Empirical Characteristics of Dynamic Trading Strategies: The Case
An Empirical Assessment of Characteristics and Optimal ...
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Current draft: November 18, 2016First draft: February 1, 2012
An Empirical Assessment of Characteristics and Optimal Portfolios
Christopher G. Lamoureux∗
andHuacheng Zhang†
Measurable stock characteristics can be used to generate positive expected returns that areorthogonal to the known factors. The cross-section of equity returns also exhibits a strongmonth-of-the-year seasonal pattern. Since returns on long-short portfolios and Fama-Macbethcharacteristic-based portfolios have relatively high variances, fat tails, and negative skew, thispaper examines the efficacy of stock characteristics to maximize a convex objective function (suchas a power utility function).
The Brandt, Santa-Clara, and Valkanov (2009) algorithm exhibits large estimation risk whichmust be solved before it can provide insight into our research question. We address this by usinghigher values of risk-aversion to select portfolios. We examine complementarity and substitutabil-ity across characteristics. We find that the book-to-market ratio is redundant in the context ofsize and market model residual standard deviation. In isolation beta appears to be unambigu-ously bad, but in combination with the market model residual standard deviation this effectvanishes. Momentum and average same-month return are independent of the other characteris-tics. The bootstrap shows that there is a high level of imprecision in the relationships betweenvectors of characteristics and the distribution of (future) portfolio returns. While beta and av-erage same-month return are effective in increasing expected utility for relatively risk-tolerantinvestors, they are dropped from the optimal set of characteristics for more risk-averse investors.
Optimal portfolios tend to be positively skewed and fat-tailed. Their exposure to the themarket factor is significantly less than unity, and they have generally positive exposure to themomentum and value factors. Optimal portfolios have high (but not maximal) Sharpe ratios,and significantly positive Fama, French, Carhart alphas. Alpha and our objective functions arequite disparate however, as those portfolio with the highest alphas are severely penalized by theobjective function’s convexity.
Key Words: Stock characteristics; optimal portfolios∗Department of Finance, The University of Arizona, Eller College of Management, Tucson, 85721, 520–621–
7488, [email protected].†Department of Finance, Southwest University of Finance and Economics, Changdu, China,
[email protected] are grateful to Scott Cederburg, Kei Hirano, and Michael Weber. The current version of this paper can bedownloaded from lamfin.arizona.edu/rsch.html .
1. Introduction
Firm characteristics can predict future stock returns in the cross-section (Lewellen 2015). The
cross-section of expected stock returns also has a strong seasonal component (Keloharju, Linnain-
maa, and Nyberg 2016). This paper analyzes these facts from the perspective of a risk-averse
expected utility maximizing investor. To what extent does this cross-sectional predictability
cause such an investor to tilt her optimal portfolio weights away from the market portfolio? This
is an open question since many alpha generating strategies entail high volatility, fat tails, and/or
negative skew (Barroso and Santa-Clara 2015). To this end, we use Brandt, Santa-Clara, and
Valkanov’s (2009) normative algorithm that allows optimal portfolio weights to depend on stock
characteristics. We consider estimation risk and optimal characteristic usage by investors with
varying degrees of risk aversion. We document the properties of these optimal portfolios in terms
of return moments and factor loadings. All of our statistical analysis is conducted out-of-sample,
using the bootstrap to conduct inference.
Lewellen (2015) notes that much of the empirical literature on characteristics and returns
uses portfolios that are formed by sorting on one, and possibly two characteristics. As such, we
have limited information about characteristics’ complementarity and substitutability–especially
as these may affect characteristics’ efficacy for optimizing investors. Because characteristics are
not independent these effects are important. For example, investors prefer low beta to high beta
stocks when beta is the only characteristic available.1 However, when we add residual standard
deviation to beta–allowing weights to depend on both–then beta becomes attractive (to risk-
averse investors with relatively high risk tolerance), and investors prefer low residual standard
deviation stocks along with higher beta stocks. We also find that the book-to-market ratio is
redundant in the context of the other characteristics that we consider: momentum, size, beta,
residual standard deviation, and lagged same-month returns. Since there is significant estimation
risk, which is mitigated by parsimony, it is never optimal to include the book-to-market ratio in
the optimal set of characteristics.
We consider nine different objective functions, or “investors”–indexed by the coefficient of
relative risk aversion (γ)–and examine how the set of optimal characteristics varies as we increase
γ. Investors with γ of 2, 3, and 4 optimally use: momentum, size, beta, residual standard
deviation, and five-year average same-month return. Investors with γ of 5, 6, and 7 drop beta
from the optimal set of characteristics. Investors with γ of 8, 9, and 10 also drop the average
same-month return–leaving only three characteristics to optimally tilt portfolio weights.
We examine in depth the estimation risk inherent in the selection algorithm. Estimation risk
1Such a result would be consistent with Frazzini and Pedersen (2015) who argue that leverage-constrainedinvestors bid up the prices of high beta stocks, which therefore have lower expected returns, ceteris paribus.
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is severe. We find that an updating protocol dominates a rolling protocol, so estimation risk in
this context is not due to slowly evolving relations between (cross-)moments and characteristics.
Instead the estimation risk that plagues this algorithm is conventional overfitting–relying too
heavily on in-sample patterns. We analyze the nature of estimation risk as a statistical problem
by comparing the out-of-sample expected utility of all portfolios selected using an investor’s own
gamma with those selected using higher values of gamma.
This effectively means that our analysis is not normative since we make statistical choices
based on “out-of-sample” results. Instead we are using portfolio selection as a descriptive ana-
lytical tool to evaluate the relationships between characteristics and portfolio returns. In what
follows we will use the word gamma to reference a statistical loss function (or “an investor”),
and the symbol γ to reference the parameter used to select the portfolio. As such we will have
a certainty equivalent for each “investor” (indexed gamma 2, . . . , 10, using all values of γ in the
integer set: {2, . . . , 13, 16, 22} for γ values greater than or equal to the “investor’s” gamma. We
find that out-of-sample, all loss functions are maximized by using a value for γ that is larger than
(the investor’s actual) gamma.
We examine the properties of the optimal portfolios for each loss function: their factor
loadings, alphas, Sharpe ratios, means, variances, skewness, and kurtosis, and how the various
characteristics affect these portfolio measures. For example, the gamma 2 investor’s optimal
portfolio, obtained using γ = 3, has a monthly alpha of 296 basis points per month, significantly
less exposure to the market, and significantly more exposure to SMB, HML, and MOM than
both the value-weighted and equally-weighted indices. The portfolio’s mean Sharpe ratio is 1.24,
almost twice as high as that of the equally-weighted index (whose mean Sharpe ratio is 0.63). This
portfolio’s skewness and kurtosis are not significantly different from those of the two benchmark
portfolios.2
Similarly the optimal portfolio for the gamma 6 investor, obtained using γ = 11, has signifi-
cantly less exposure to the market and significantly more exposure to HML and MOM than the
benchmarks. However, this portfolio has insignificant exposure to SMB. This portfolio’s mean
Sharpe ratio is 1.27, and it has significantly more positive skewness and kurtosis than the bench-
marks. The optimal portfolio for the gamma 10 investor also has significantly less exposure to
the market and significantly more exposure to HML and MOM than the benchmarks. It has
significantly negative loading on SMB. Its mean Sharpe ratio is 1.07, and it also has significantly
more positive skewness and kurtosis than the benchmarks. This portfolio also has a statistically
significant alpha of 49 basis points per month. While this portfolio’s return standard deviation
2The equally-weighted and value-weighted benchmarks are portfolios that are formed from the (eligible sample)set of securities. We avoid using the term index to characterize these portfolios because they are different fromthe Fama French value-weighted index which we use as a factor.
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is larger than that of the value-weighted index, its interquartile range is statistically significantly
smaller.
Bootstrapping highlights the lack of precision in the role for characteristics. Much of this is
due to the complementarity between the characteristics as we show that adding characteristics
generally decreases the precision of the coefficients that relate portfolio weights to characteris-
tics. Furthermore estimation risk increases in the dimensionality of the set of characteristics
used. Lewellen, Nagel, and Shanken (2010) stress the importance of examining this precision.
Nevertheless the benefits of using characteristics to tilt portfolio weights transcend this impreci-
sion. The approach in this paper addresses several of Lewellen, Nagel, and Shanken’s concerns
about traditional tests. In particular we use individual stock returns and we only evaluate the
out-of-sample performance of the optimal portfolios.
We examine the month-of-the-year properties of the optimal portfolios. Lagged same-month
return is largely independent of the other characteristics, and calls attention to the possibility
that optimal portfolios’ exposures to risk factors may vary across the 12 months of the year. We
summarize this by looking at the bias in alpha from the Fama, French, Carhart regressions that
is due to assuming that the factor loadings are the same across the 12 months. We decompose
this bias into risk-premium exposure and volatility exposure. Referring to the optimal portfolio
for the gamma 2 investor (with mean alpha of 296 basis points per month), the mean calendar
bias is 46 basis points per month. The largest portion of this bias is due to volatility timing of
the SMB factor.3 That is the portfolio loads more heavily on SMB in months when SMB has
higher volatility than in other months.4
Ultimately we add to what we know about the predictive content of characteristics for con-
structing optimal portfolios. Just as they are useful in predicting expected returns, they can
be used to form portfolios with significantly higher certainty equivalent returns than the value-
weighted and equally-weighted indices.5 Complementarities are extremely important to under-
stand the optimal role of beta and size. Substitution effects are important to understand the role
of the book-to-market ratio, which we find to be redundant. Risk averse investors want exposure
to SMB, HML, and the momentum factor. In particular exposure to the momentum factor re-
3We use the measures of volatility timing and factor exposure timing from Boguth, Carlson, Fisher, and Simutin(2011).
4This is artifactual as is the portfolio’s alpha itself (that is the algorithm is not trying to maximize alpha, perse). In the sense that we do not know a priori whether alpha in the Fama, French, Carhart regressions is desirableto the CRRA investors. We find that the alphas of those optimal portfolios selected using only lagged same-monthreturns have a very large month-of-the-year timing bias component. For example, when γ = 2 is used to select theoptimal portfolio, and the only characteristic is 5-year average same-month return, the portfolio’s mean alpha is211 basis points per month, of which 92 basis points is timing bias, and 77 basis points of that is due to volatilitytiming biases which are statistically significant on the market, SMB, and HML.
5This provides contrast to the optimality of equal weighting as a robust rule for portfolio formation, as shownby DeMiguel, Garlappi, and Uppal (2009).
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duces the out-of-sample occurrence of very large negative returns that occur when momentum is
excluded from the characteristic set. The only characteristic that allows the investor to control
portfolio exposure to the momentum factor is the stock’s momentum. Similarly the only way
investors can regulate their exposure to SMB is with the size characteristic. However, investors
do not need the book-to-market characteristic to achieve optimal exposure to HML. This can be
obtained using log size and residual standard deviation.
The remainder of the paper is organized as follows. We describe the data and empirical ap-
proach in Section 2. Summary results concerning the algorithm and estimation risk are provided
in Section 3. Section 4 contains a discussion of the paper’s empirical findings. Section 5 concludes
the paper.
2. Portfolio Selection
2.1 Algorithm
In Brandt, Santa-Clara, and Valkanov’s (2009) algorithm, investors choose the vector θ in
order to maximize average utility over T periods:
maxθ
T−1∑t=0
(1 + rp,t+1)1−γ
1− γ
(1T
)(1)
by allowing the weights to depend on observable stock characteristics:
rp,t+1 =Nt∑i=1
(ωi,t +
1Ntθ′xi,t
)· ri,t+1 (2)
Where: xi,t is the K-vector of characteristics on firm i, measurable at time t; ωi,t is the weight
of stock i in the (value-weighted) market portfolio at time t; and Nt is the number of stocks in
the sample at time t.6 An alternative perspective on this loss function is that it is asymmetric
in the portfolio’s return. It would be relevant for an institutional money manager who wants to
avoid large losses in a single month.
2.2 Data
An observation of stock i at time t consists of the return in month t + 1 and the set of
characteristics that are measurable at time t. We use the following characteristics: momentum
(M), book-to-market (V), size (S), beta (β), market model residual standard deviation (σε), and
rt−12, and rt−12j , for j = 1, . . . , 5. Momentum is measured as the compounded return from
month t − 13 though t − 2. Market capitalization is the market value of all of a company’s
6We condition only on information that is available to investors at the time the portfolios are formed. Thisavoids the overconditioning bias analyzed by Boguth, Carlson, Fisher, and Simutin (2011).
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outstanding shares (aggregated across all classes for companies with multiple share classes) at
time t− 2. Book value is obtained from the Compustat database for the most recent fiscal year-
end between t − 6 and t − 18. The book-to-market ratio is the ratio of book value to market
capitalization. Size is the natural logarithm of market capitalization. Beta and the residual
standard deviation are obtained by regressing monthly returns from months t− 60 through t− 1
on the CRSP value-weighted index. All characteristic and return data is drawn from the merged
CRSP-Compustat file on WRDS. To be eligible for inclusion in the sample in month t, the stock
must have no missing returns in the CRSP database for the previous 60 months, and it must
have book value information in the Compustat database for a fiscal year-end between t− 6 and
t − 18. We obtain the US GDP deflator from the Federal Reserve (FRED) and use this to
construct a minimum size criterion of $50 million in January 1990 dollars. Stocks whose market
capitalization is less than this inflation-adjusted size criterion are excluded from the sample. This
excludes stocks with market capitalization less than $11.5 million in January 1960, and $93.3
million in December 2015. We next exclude the smallest 10% of stocks that meet all inclusion
criteria prior to February 1978, when the first Nasdaq stocks enter the sample, and the smallest
20% afterwards. If the stock return is missing in month t, we look to the CRSP delisting return.
If that is missing, we substitute -30% for NYSE- and AMEX-listed stocks and -50% for Nasdaq
stocks.
Figure 1 shows the sample size used each month. There are 395 (exclusively New York Stock
Exchange-listed) stocks in the sample in January 1960. There is a jump in the sample size
in August, 1967 (from 675 to 875) when the American Stock Exchange stocks are eligible for
inclusion in our sample. The largest jump is in January 1978 (from 1,000 to 1,419 stocks) when
Nasdaq stocks enter our sample. The maximum number of stocks is 2,291 in April, 2006. There
are 1,728 stocks in our sample in the last month, December 2015.
As noted, we normalize and standardize the characteristics–ensuring that the weights will sum
to unity for any value of θ. This also means that the characteristics are observationally equivalent
to shrinkage values. For example, let β be a stock’s OLS beta, were we to use shrinkage betas,
such as βS = .5·β+.5·1, the normalized βS are identical to the normalized β. A single observation
(Ψi,t) comprises stock i’s return in month t, ri,t, as well as the vector of characteristics, measurable
at month t− 1, for stock i, i = 1, . . . , Nt.
2.3 Specifications
A model is defined by the (sub-)set of characteristics used in portfolio selection. We consider
41 models which include each of the six characteristics as a singleton, and all seven variables
together. We consider 14 values of γ, which means that we evaluate 574 unique portfolios.
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Empirical analysis of the portfolios selected using the expected utility optimizing algorithm must
be conducted out-of-sample. We use both a rolling and updating protocol. The first out-of-
sample month is January 1975. At this point we have estimated the θ-vector using 180 months
of data. As in Brandt, Santa-Clara, and Valkanov (2009), we use this θ-vector construct the
optimal portfolios in each of the next 12 months. We add the 12 months of 1975 to the original
180 months under the updating protocol, whereas we drop the first 12 months in the last sample
(i.e., the 12 months of 1960) under the rolling protocol to estimate the θ-vector to use in forming
the optimal portfolios in 1976. The last out-of-sample year is 2015, so the last optimization/θ
estimation (applied to the 12 months of 2015, out-of-sample) uses 660 months under the updating
protocol (and the 180 months of 2000 – 2014 under the rolling protocol). This means that we
optimize utility (and estimate the θ vector) from each of the 574 cases 41 times–at the end of
each in-sample period. The out-of-sample period comprises the 41 years 1975 – 2015.
2.4 The bootstrap
Our interest is in statistical comparisons across various models. We use the bootstrap to
construct sampling distributions of the functions of interest in this paper, such as certainty
equivalent, portfolio loading on factors, portfolio skew, etc. The bootstrap also shows that
there is a small sample bias in the θ estimates, and other functions of θ. Our bootstrap is
designed as follows. As noted the data in month t in our sample consist of the Nt vectors
Ψi,t, for i = 1, . . . , Nt and t = 1, . . . , 672. A bootstrap draw resamples (with replacement) Nt
vectors from Ψi,t in all months. Thus each bootstrapped sample consists of the same number
of observations in each period as the original sample, and the calendar structure of the original
data is preserved. The latter is important because we consider the possibility that the 12 months
of the year are important characteristics. We take 10,000 bootstrap samples to estimate the
sampling distributions for all 574 unique portfolios.7
3. Algortithm efficacy and estimation risk
Table 1 reports the model with the highest bootstrap 2.5%ile certainty equivalent (across
the 41 specifications) for each of the nine investors, for her own and all higher γ values used to
estimate θ. The first row under each γ value is the result of using the updating protocol and
the second row is for the rolling protocol. This table also reports the bootstrap and sample
values of the certainty equivalent for both the equal- and value-weighted indices for all investors.
This table is excerpted from Tables IA-1 through IA-9,8 which report the bootstrap distributions
7The computational burden is non-trivial. A typical bootstrap takes 26 hours of CPU time on a 3.7 GHzXeon processor. However, since the bootstrap draws are independent (unlike in Markov Chain Monte Carlo, forexample), the algorithm is easily parallelizable.
8Tables starting with IA are collected in this paper’s Internet appendix.
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and sample estimates of the certainty equivalent for each of the nine investors, respectively,
using each value of γ and all 41 models under the updating protocol. That combination (of γ
and characteristic set) that produces the maximum 2.5%ile value of the certainty equivalent is
highlighted in bold face.
For example, the gamma 2 investor’s median certainty equivalent for the value- (equally-
weighted) index is 106 (86) basis points per month. When this investor uses her own γ, the model
(i.e., the set of characteristics whose θ is not restricted to equal 0 in all periods) with the highest
2.5%ile certainty equivalent is that comprising momentum, book-to-market, and size, using the
updating protocol. The gamma 2 investor does not prefer this portfolio to the equally-weighted
index, on a statistical basis. Such a preference requires that the 2.5%ile certainty equivalent
value of the preferred portfolio exceed the alternative portfolio’s 97.5% certainty equivalent. A
glance at Table IA-1 shows the nature and severity of the estimation risk problem in this case.
All 11 portfolios selected using five or more characteristics have a 2.5%ile certainty equivalent
of -100%. This means that in at least 250 of the bootstrap samples, the portfolio lost at least
100% of its value in at least one month in the out-of-sample period. This is also the case with all
models that include last year’s same-month return regardless of the number of characteristics.
Table 1 also shows that estimation risk is extenuated by using the rolling protocol. Using
γ = 2, the 2.5%ile certainty equivalent return (as well as the 25%ile certainty equivalent) of all
41 models is -100% for the gamma 2 investor.
By contrast, when the gamma 2 investor uses γ = 3 along with the characteristics: momen-
tum, log size, beta, residual standard deviation, and (lagged) 5-year average same-month return;
and the updating protocol to estimate θ, the median certainty equivalent is more than three
times higher than that of the equally-weighted index, and the 2.5%ile is 288 basis points per
month. Table IA-1 makes clear that using γ = 3 is not a panacea for the gamma 2 investor,
as nine of the 41 models produce a 2.5%ile certainty equivalent of -100%, including most that
contain last year’s same-month return. Table IA-1 also demonstrates the imprecision with which
the coefficients interact with portfolio moments. There are five additional models that are not
statistically dominated by the optimal. That is the 2.5%ile certainty equivalent exceeds the
97.5%ile of the equally-weighted index and the 97.5%ile exceeds the 2.5%ile of the the optimal
portfolio’s certainty equivalent. For example, adding book-to-market to the characteristic set
lowers the 2.5%ile certainty equivalent by 25 basis points per month, but increases the median
and 97.5%ile. The optimal model significantly dominates all (19) of the sets of characteristics
involving three or fewer characteristics. Table IA-1 also shows that using the optimal set of
characteristics and higher values of γ produces portfolios that are not statistically worse for the
gamma 2 investor. Increasing γ by a factor of one reduces the mean certainty equivalent return
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by 20 basis points. For γ values of 8 and higher, the optimal portfolio is statistically dominated
by the optimal portfolio selected using γ = 3.
Table IA-1 shows that including momentum in the set of characteristics is important to
reduce estimation risk. For the gamma 2 investor using γ = 3, and all sets of four, five, and six
characteristics that do not include momentum, the optimal portfolio’s 2.5%ile certainty equivalent
return is -100%. For example when the book-to-market ratio is substituted for momentum in
the characteristic set, the mean certainty equivalent drops from 336 to -1,230 basis points per
month. Adding last year’s same-month return to this set of characteristics further exacerbates
estimation risk. Even dropping momentum from the set of optimal characteristics, leaving log
size, beta, residual standard deviation and lagged average same-month returns results in an
optimal portfolio whose 2.5%ile certainty equivalent return is -100% when γ = 3 is used to
estimate θ. The optimal portfolio using all (six) characteristic variables excluding momentum
has a mean certainty equivalent of -6,045 basis points per month, when γ = 3. The mean certainty
equivalent using this set of characteristics is also negative for the gamma 2 investor, using a γ
value as high as 5 to select the optimal portfolio. As we will show below, adding momentum
to the other four characteristics increases the mean minimum (monthly) return on the optimal
portfolio using γ = 3 from -79% to -52% by significantly increasing the portfolio’s exposure to
the momentum factor. This is the reason that adding the momentum characteristic to the other
four characteristics has such a large effect on the optimal portfolio’s certainty equivalent return.
Using γ = 3 with the rolling protocol does not produce any optimal portfolios that allow the
gamma 2 investor to dominate the benchmarks. In fact, Table 1 shows that for this investor the
optimal result under the rolling protocol requires the use of γ = 5, and all 7 characteristics. This
portfolio also statistically dominates the benchmarks, and is not statistically dominated by the
global optimum portfolio for the gamma 2 investor (from the updating protocol, as its 95%ile
sampling interval certainty equivalent return is [248 , 366] (basis points per month). Table 1
shows that the optimal γ to use is also not precise, as the gamma 2 investor’s optimal portfolio
is not statistically dominated by the global optimum for γ values of 4, 5, 6, and 7. Table IA-1
also shows that in these cases, adding book-to-market and last year’s same-month return to the
five variables in the original optimal set has a trivial (and statistically insignificant) effect on the
optimal certainty equivalent returns.
The nature of the optimal portfolios and estimation risk for the gamma 3 and gamma 4 in-
vestors are very similar to that of the gamma 2 investor. The equally-weighted index statistically
dominates the value-weighted index for these investors. The gamma 3 investor’s optimal portfolio
is achieved using γ = 5 and the gamma 4 investor optimally uses γ = 7. The optimal character-
istic set for these two investors is the same as for the gamma 2 investor: momentum, log size,
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beta, residual standard deviation, and (lagged) average same-month return. The proportional
gains in certainty equivalent returns for these investors are also similar to that of the gamma 2
investor. The gamma 4 investor increases certainty equivalent mean return from 77 basis points
per month to 199 basis points per month using these five characteristics to tilt portfolio weights
away from the market portfolio–versus the 1/N rule. The rolling protocol has more estimation
risk. The gamma 4 investor for example has to increase γ to 9 to maximally reduce estimation
risk under the rolling protocol. The optimal portfolio in this case also significantly dominates
the equally-weighted index and is not dominated by the global optimal portfolio. For all three
of these investors the optimal portfolio under the rolling protocol is obtained using all seven
characteristic variables, and that under the rolling protocol drops the book-to-market ratio and
last-year’s same-month return from this set.
The gamma 5 and gamma 6 investors are statistically indifferent between the equally-weighted
and value-weighted indices and the gamma 7 investor prefers the value-weighted index. These
three investors optimally use the same characteristic set under the updating protocol: momentum,
log size, residual standard deviation, and average same-month return, so that beta is dropped
from the set used by more risk-tolerant investors. For these three investors the rolling protocol
is strictly dominated by the updating protocol, since all of the optimal portfolios generated by
the former are significantly dominated by those from the latter. The magnitude of the utility
gain for these investors is similar to that of the less risk-averse group. For example the gamma
7 investor’s mean certainty equivalent increases from 34 to 116 basis points per month switching
from the value-weighted index to the optimal portfolio, which is obtained using γ = 13.
The gamma 8, gamma 9, and gamma 10 investors comprise the third set of investors. All
three of these investors optimally use γ = 16 (since the grid of γ used to obtain portfolios is not
continuous), and the optimal set of characteristics is: momentum, log size, and residual standard
deviation. For these investors the rolling protocol is also optimized using these three character-
istics and γ = 16 (with very similar results using γ = 13). These optimal rolling portfolios are
not significantly dominated by the optimal portfolios produced under the updating protocol.
Overall the relationship between the updating and rolling protocols means that slowly evolv-
ing relationships between the (multivariate) return distribution and the characteristics is not
driving estimation risk–in the context of the optimal set of characteristics. Nor are there im-
portant structural breaks in these relationships. If there were, then the rolling protocol would
yield portfolios that outperform those selected using the updating protocol. The rolling proto-
col’s underperformance–relative to updating–also suggests that in the multivariate context there
is no evidence of a diminution of the predictive content of the characteristics over time, as in
Mclean and Pontiff (2016). Although Mclean and Pontiff evaluate long-short portfolios using one
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characteristic at a time. We see below that the evidence is different for singleton characteristic
sets than for multivariate sets of characteristics.
Estimation risk increases in the dimensionality of the characteristic set, with the exception
that adding momentum always mitigates estimation risk. In what follows we will consider how
momentum affects the factor exposure and moments of the optimal portfolios to consider its
effect on estimation risk in more detail.
It is never optimal to include last-year’s same-month return in the characteristic set. This is
because in the context of the five-year average same-month return this is very noisy and results
in increased estimation risk. The optimal portfolio also never conditions on the book-to-market
ratio. We will show below that this is not because these portfolios are not exposed to the HML
factor, but instead that size and residual standard deviation provide enough flexibility to allow
optimal exposure to the value factor. In other words the book-to-market ratio is redundant and
adds estimation risk.
The estimation risk in this context then is conventional overfitting. This inference is also
consistent with the fact that the dimensionality of the optimal model shrinks as investor risk
aversion increases. Those investors with gamma values higher than 5 eschew beta, and those
with gamma values higher than seven also drop the average same-month return from the optimal
characteristic set. The benefits delivered by these characteristics to lower gamma investors are
offset by estimation risk for the more risk-averse investors.
These results suggest that θ shrinkage or even holding a larger portion of assets in cash and/or
the market is also not optimal. In most cases, the adjustment involved with using a higher γ
than in the actual utility function is to lower the exposure to the characteristic (i.e., θ shrinks in
absolute value), but this is not the case when characteristics are optimally removed from the set
used to estimate θ. We will revisit this as well when we evaluate the θ coefficients below.
4. Characteristics and portfolios
4.1 Characteristics in isolation
Tables IA-1 – IA-9 show that momentum, book-to-market, and log size never serve as a single-
ton characteristic to produce significantly higher certainty equivalent–for any investor, using any
γ value. The most risk-tolerant investors (those whose coefficient of relative risk aversion is two
and three) can use the average same-month return by itself to create portfolios with significantly
higher certainty equivalent than the equally-weighted benchmark. Investors with midlevels of risk
aversion (those with coefficients of relative risk aversion between five and eight) can significantly
increase certainty equivalent above the benchmark by using the residual standard deviation in
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isolation. Investors with high risk aversion (those with coefficients of relative risk aversion be-
tween seven and nine) can significantly increase certainty equivalent above the benchmark by
using beta in isolation. Therefore, most–and in some cases all– of the (out-of-sample) utility
gains from using the characteristics in combination.
4.2 Substitutions and complementarities
Whereas momentum and log size never generate such a portfolio in isolation, both of these
characteristics–along with the residual standard deviation–are used in the optimal characteris-
tic set for all nine investors. Therefore the salutary effects of the characteristics for risk-averse
utility optimizing investors is primarily due to substitution and complementary effects between
the characteristics. This fact belies traditional analysis of the role of characteristics and returns,
which has focused mainly on the relationship between characteristics and expected returns, and
has generally analyzed these effects one characteristic at a time (Lewellen 2016). Another im-
portant difference between this approach and much of the literature is that this analysis has to
be out-of-sample (since the model places no testable restrictions on the data generating process),
(Lewellen, Nagel, and Shanken 2010).
Tables IA-10 through IA-16 report bootstrap properties for θ coefficients on each of the seven
characteristic variables for all the optimal portfolios produced under the updating protocol, from
all of the combinations of characteristic sets that contain that variable, for all 14 γ values. Table
2 shows the sampling distributions of the average of the 41 annual θ coefficients on the (seven)
portfolios that are optimal for the nine investors. Figures 2 – 6 show bootstrap properties of the
estimated θ coefficients by year (41 years: 1974 through 2014, used to form the out-of-sample
portfolios in the following year). We show each of the five characteristic variables that enter
the optimal set for the gamma 2, 3, and 4 investors, when they are used in isolation(top panel),
and in the optimal portfolio using γ = 3 (lower panel). Figure 2 shows the bootstrap properties
of the θ coefficients on momentum. When momentum is used in isolation, there appears to be
a structural break after year 25, so we split the results temporally at this point in the tables.
Comparing the two panels in Figure 2 it is clear that the sampling distribution of the estimated
θ is much tighter when momentum is the only characteristic. This is also evident in Table IA-10
as the standard deviation of the momentum θ in the second period (Years 26 - 41) is 0.18, when
momentum is the only characteristic used, and 0.40 when momentum is used along with: log size,
beta, residual standard deviation, and average same-month returns. Also the imprecision in the
latter case is such that there is no evidence of a structural break in the momentum θ coefficient
in the optimal model for the gamma 2 investor.
The figures also report the sample estimate of θ in the context of the parameter’s bootstrap
11
distribution. These coefficients are biased (away from zero). This bias is extenuated by dimen-
sionality of the sample space, and in most cases appears to get worse over time.9 These biases
support our use of bootstrap means instead of the sample estimates for our statistical analyses.
These biases also explain the differences between the bootstrap mean certainty equivalent and
the sample value, shown in Table 1 as well as Tables IA-1 – IA-9. The sample certainty equivalent
for the gamma 2 investor’s optimal portfolio is 376.4 basis points per month, above the bootstrap
75%ile value.
Momentum enters the optimal characteristic set for all nine investors. For the gamma 8, 9,
and 10 investors the mean θ coefficient on momentum is 1.54 in 1975 - 1999 and 0.91 in 2000
- 2015. The difference between these is statistically significant. These momentum θ coefficients
are not significantly different from the optimal θ values for the gamma 6 and 7 investors, but
they are significantly smaller than the optimal θ for those investors whose gamma is less than 6.
Figure 2 shows that momentum is largely independent of the other characteristics since the
levels of θ are similar when momentum is used in isolation, as when it is part of the optimal
characteristic set. There appears to be some evidence of complementarity in the latter part of
the sample. In this period, the 95% sampling interval of the momentum θ used in isolation is
[2.62 , 3.32], whereas in the optimal set this interval is [3.87 , 5.44].
Figure 3 and Table IA-12 report properties of the θ coefficient on log size. As with momentum,
the figure shows that the sampling distributions are much less precise in the higher dimensional
case. The sample bias is also worse in this context, and at the end of the sample. This figure and
table show that size is complementary to the other characteristics. In isolation, the 95% sampling
interval of the θ coefficient on log size in the two periods are: [−3.0 , −1.7] and [−2.5 , −1.6],
respectively. By contrast, in the optimal model for the gamma 2 investor, these ranges are:
[−13.7 , −9.6] and [−10.7 , −8.3], respectively. We can look at all of the specifications reported
in Table IA-12 to isolate which characteristic(s) are most complementary to log size. Adding the
book-to-market, momentum, and same-month returns, individually or in combination have no
effect on the log size θ. Beta, like residual standard deviation, tends to complement log size, and
the effects of these two are distinct.
Table IA-13 and Figure 4 show properties of the θ coefficient on beta. When beta is the
only characteristic (top panel in both Figure 4 and Table IA-13) the θ coefficient is significantly
negative for all gamma values used to select the optimal portfolio in both subperiods. Further,
there is no statistical difference between the coefficients as γ ranges from 2 through 22. Such9This suggests that a bias adjustment technique such as bootstrap aggregation (or “bagging”) might improve
matters in terms of selecting optimal portfolios. Experimentation with both bagging and bragging suggests thatthe methods produce small gains in certainty equivalent that are orders of magnitude smaller than the gainsachieved with simply using a higher γ to select the optimal portfolio. The numerical demands of such techniquesare also overwhelming.
12
a result is consistent with Frazzini and Pedersen (2016), who argue that high beta stocks are
bid-up by borrowing-constrained investors, so that they offer lower expected rates of return after
adjusting for risk. If this were indeed the case, then the appeal of low beta stocks in this setting
would be independent of the investor’s risk aversion, since we assume away borrowing constraints.
This result is not robust. All of the portfolios formed by conditioning only on beta (and which
have an average negative θ coefficient on beta) are dominated by the optimal portfolio for all
investors. For the gamma 2, 3, and 4 investors these involve a statistically insignificant θ in the
first 25 years and a significantly positive θ coefficient on beta in the 2000 – 2015 period. For the
more risk-averse investors with gamma values 5 and higher, these optimal portfolios place a 0
weight on beta. Table 2 shows that the average coefficient on beta is not statistically different
from 0 over the full 41 year period. This is also evident in Figure 4. Despite this, investors with
gamma values of 4 and lower are better off including beta in the set of characteristics, which
speaks to the time-series properties of beta. Clearly the coefficient on beta is significantly positive
in the latter 16 years of the sample (Table IA-13).
Table IA-13 shows the effects of adding the other characteristics to beta: the residual standard
deviation, momentum, and log size are the sources of complementarity with beta. In particular,
adding residual standard deviation to beta leads to a positive θ on beta in both periods, using
γ = 2, and in the 2000–2015 period using γ ≤ 5. This suggests that beta is correlated with
something that all investors do not like. And the residual standard deviation is also correlated
with this latent factor. Kogan and Papanikolaou (2013) argue that firms with higher idiosyncratic
volatility have higher growth opportunities, and lower risk premia. When relatively risk-tolerant
investors condition on both beta and the residual standard deviation, the residual standard
deviation allows them to reduce their exposure to this factor, and then higher beta stocks are
more attractive than low beta stocks. The fact that beta is dropped from the optimal set of
characteristics when investor gamma is 5 and higher suggests that it has a lot of estimation risk,
and that its appeal in-sample does not produce benefits out-of-sample.
Figure 4 shows one reason for isolating the period 2000-2015, as the θ coefficient on beta–
when beta is used in isolation–behaves differently over this period than in the preceding period.
The figure also shows that the bias in the sample θ coefficient is larger when beta is combined
with the four other characteristics than when it is used in isolation.
Table IA-14 and Figure 5 report the properties of the θ coefficient on the residual standard
deviation. The figure shows that for the gamma 2 investor, the coefficient on the residual standard
deviation is uniformly negative, and that this is complemented by the other characteristics,
especially size and beta. For example, the average θ coefficient on the residual standard deviation
for the gamma 2 investor using γ = 3 when residual standard deviation is the only characteristic
13
is -2.0. In the optimal model, this average bootstrap coefficient is -11.89. The residual standard
deviation, like momentum and log size is optimally used by all investors, and has a significantly
negative θ coefficient in all optimal portfolios. Figure 5 shows that as the case with the other
characteristics the sample bias is extenuated by the model dimensionality and the increased
sample size. Table IA-14 shows that the θ coefficient on this characteristic is much more sensitive
to investor risk aversion when it is used in combination with size and beta, but it is significantly
negative in all optimal portfolios.
Table IA-15 and Figure 6 show properties of the θ coefficient on lagged five-year average
same-month return. Table IA-15 shows that the θ coefficient on this characteristic is significantly
higher in the second subperiod in the optimal models for the gamma 3, 4, 5, 6, and 7 investors
than in the model in which it is the only characteristic. The 95% sampling bands on the θ
coefficient on rt−12j in the two subperiods for the optimal portfolio for the gamma 6 investor
(using γ = 11) are: [1.7 , 3.3] and [1.9 , 3.0], respectively. When rt−12j is the only coefficient in
the characteristic set, these bands are [1.2 , 2.1] and [0.6 , 1.2], respectively, when γ = 11. This
means that in the second subperiod, for investors whose gamma exceeds 2, momentum, log size,
and residual standard deviation are complementary to lagged same-month return. Figure 6 shows
that when rt−12j is used in isolation the θ coefficient varies significantly from year to year (which
is also apparent in significant differences between the two subperiods for this model). The lower
panel of Figure 6 shows that this is not the case for the optimal model for the gamma 2 investor,
largely because the sampling variances on these coefficients are so large.
Two of the seven characteristic variables, last-year’s same-month return (whose θ coefficients
are reported in Table IA-16) and the book-to-market ratio are not used in any of the optimal
portfolios. Tables IA-1 – IA-9 show that for the most part this is because of redundancy and
estimation risk, rather than direct harm. Adding both characteristic variables to the optimal set
for the gamma 4 investor results in an insignificant drop in the certainty equivalent; the 95%ile
bands on the certainty equivalent decrease from [173 , 226] to [157 , 223] (basis points per month).
Adding a characteristic which is largely spanned by the other characteristics adds estimation risk,
seen in the drop in the 2.5%ile of the sampling distribution in these cases.
5. Portfolios and Factors
5.1 Factor loadings
In this subsection we consider what these optimal portfolios’ exposures are to the traditional
risk factors as well as their alphas. Table 3 contains the results of these regressions for the
benchmarks and the optimal portfolios for the nine investors. The results for all portfolios are
14
contained in Tables IA-17 – IA-30, for each of the 14 γ values used in portfolio selection. The
exposure to the market portfolio is constant across levels of investor risk-aversion. All seven of
the optimal portfolios have loadings on the market that are significantly less than the equally-
weighted and value-weighted benchmarks.
The optimal portfolios’ exposure to SMB decreases in risk-aversion. The gamma 2 investor
has the largest exposure to this factor, with a 95% sampling band of [0.6 , 1.5]. This is significantly
larger than the equally-weighted benchmark. The gamma 3 investor’s optimal portfolio also has
significant positive loading on SMB, however this is not significantly different from the exposure
of the equally-weighted benchmark to this factor. The gamma 4 investor’s optimal portfolio also
has significant positive loading on SMB, but this is significantly less than the exposure of the
equally-weighted benchmark to SMB. The optimal portfolios of the gamma 5, 6, and 7 investors
have insignificant exposure to SMB, and none of these are significantly different from the value-
weighted benchmark’s SMB loading. The optimal portfolio for the most risk-averse investors
with gamma values of 8, 9, and 10 are significantly negative, although not significantly different
from the value-weighted benchmark.
All of the seven optimal portfolios have significant positive exposure to HML, as does the
equally-weighted benchmark. All of the portfolios’ loadings on the HML factor exceed that
of the equally-weighted benchmark, and decline only slightly in risk-aversion. The gamma 2
investor’s optimal portfolio has a significantly higher loading on HML than the optimal portfo-
lios of investors with gamma of 4 or higher. The optimal portfolio of the gamma 4 investor’s
loading is not significantly different from that of investors with gamma between 5 and 8. The
value-weighted benchmark has no exposure to the momentum factor and the equally-weighted
benchmark has significantly negative exposure to this factor. All of the optimal portfolios have
significant exposure to this factor. The momentum loading decreases in investor risk aversion.
Tables IA-17 – IA-30 provide evidence about the linkages between the characteristics and
factor loadings. Consider the 41 portfolios used by setting γ = 3 (which include the optimal
portfolio for the gamma 2 investor) shown in Table IA-18. When beta is the only characteristic,
the optimal portfolio has significantly less exposure to the market factor than the two benchmarks.
This portfolio has a significant negative loading on SMB, a significant positive loading on HML, as
well as a significantly positive loading on momentum. Conditioning on only the residual standard
deviation similarly reduces the exposure to the market portfolio below that of the benchmarks.
The negative weight on this characteristic implies a large negative loading on SMB, as large
stocks tend to have lower residual standard deviations. This characteristic also affords exposure
to HML. Conditioning only on the average same-month return induces a significant increase in
exposure to the market factor, and significant negative loadings on SMB and HML. None of the
15
optimal portfolios are created by conditioning on the book-to-market ratio. When we replace
momentum in this investor’s characteristic set with the book-to-market ratio, the portfolio’s
exposure to HMB is unchanged. The 95%ile sampling band of the HML loading with the book-
to-market ratio in the characteristic set is [1.4 , 2.2]; when we replace the book-to-market ratio
with momentum in the characteristic set this band is [1.4 , 2.2]. Adding the book-to-market ratio
to the five optimal characteristics does not produce a significant difference in the factor loadings,
which is not surprising as this portfolio’s certainty equivalent is not significantly different from
the optimal portfolio’s.
The most risk-averse investors optimally include only momentum, log size, and residual stan-
dard deviation in their optimal characteristic set, and use γ = 16. Table IA-29 shows that
substituting the book-to-market ratio for size in this optimal characteristic set, portfolio expo-
sure to the market factor increases significantly: 95%ile sampling bands go from [0.56 , 0.65] to
[0.76 , 0.82]. The exposure to SMB decreases from [−0.25 , −0.06] to [−0.65 , −0.52]. The two
portfolios’ exposures to HML are not significantly different. Since momentum is largely indepen-
dent of the other characteristics these results identify the complementarity between log size and
residual standard deviation.
The gamma 5 investor drops beta from the optimal characteristic set. Comparing the optimal
portfolio factor loadings for the gamma 4 investor with those of the gamma 5 investor’s optimal
portfolio shows that the effect of removing beta is virtually nil. The mean loading on the market
factor is identical after removing beta, and the sampling variance of this exposure is lower.
Comparing the optimal portfolio of the gamma 7 investor with that of the gamma 8 investor
shows the effect of removing the average same-month return from the optimal characteristic set.
The mean loadings between these two portfolios are virtually identical, and the sampling variance
is lower on all.
Table IA-20 shows that using average same-month return in isolation along with γ = 5, loads
more heavily on the market than the equally-weighted benchmark. In Section 4.1 we saw that this
portfolio has a significantly higher certainty equivalent than this higher benchmark for the gamma
2 and gamma 3 investors. The 95% sampling band of this portfolio’s loading on the market factor
is [1.16 , 1.27] . This portfolio also has significant negative exposure to SMB [−0.31 , −0.14] and
HML: [−0.35 , −0.19]. The equally-weighted index has significant positive loadings on these two
factors. The optimal portfolio selected using γ = 10 and the residual standard deviation in
isolation (Table IA-25) has significantly lower exposure to the market factor [0.75 , 0.80] than
the market benchmarks. It also has significantly negative exposure to SMB [−0.70 , −0.61]. Its
exposure to HML [0.42 , 0.50] is significantly higher than the value-weighted benchmark.
The desired exposure to HML is achieved with momentum, size, and the residual variance.
16
Table IA-24 shows the effect of adding the book-to-market ratio to the optimal set of character-
istics for the gamma 5 investor (using γ = 9). The optimal portfolio conditions on momentum,
size, residual variance, and average same-month return. Its mean exposure to the momentum
factor is 0.63 ([0.54 , 0.72]) and to HML, 1.17 ([1.03 , 1.31]). Adding the book-to-market ratio
does not significantly affect the portfolio’s HML exposure: 1.33 ([1.16 , 1.51]), but it significantly
decreases its exposure to the momentum factor: 0.41 ([0.32 , 0.51]). Kogan and Papanikolaou
(2013) provide the rationale for the residual standard deviation to regulate portfolio exposure
to the value factor, HML. In their model firms with higher growth options have higher market
model idiosyncratic volatility.
5.2 Alpha
Table 3 and Tables IA-17 – IA-30 also report the sampling values and bootstrap properties
of the intercepts from the Fama, French, Carhart regressions in basis points per month. The
maximum 2.5%ile alpha value of 371 is realized when the characteristic set comprises the book-
to-market ratio, log size, beta, residual standard deviation, last year’s same-month return, and
the average same-month return; that is all characteristic variables except momentum. This
portfolio’s mean alpha is 480 basis points per month. Table IA-1 shows that this portfolio’s
mean certainty equivalent for the gamma 2 investor is -9,305 basis points per month–highlighting
the fact that maximizing expected utility is not pari-passu with maximizing alpha. Indeed, in
general adding momentum to a characteristic set reduces the portfolio alpha, however all optimal
portfolios include momentum in the characteristic set.
Focusing on the optimal portfolios, Table 3 shows that alpha declines monotonically in in-
vestor gamma. This means that while these returns are orthogonal to the four Fama, French,
Carhart factors they are not a free lunch. It also provides an example of Ferson’s (2013) observa-
tion that a positive alpha strategy may be increasingly leveraged to further increase alpha (unlike
the Sharpe ratio, which is largely unchanged in leverage). The large drop from the gamma 7 to
the gamma 8 investor also highlights the usefulness of lagged same-month returns in producing
alpha (Heston and Sadka 2009). This is the only case in Table 3 where an adjacent portfolio
alpha is statistically different from its predecessor. While the characteristic same-month return
is related to future expected returns, this relationship is noisy enough to deter those investors
with gamma 8 and higher from exploiting this predictive content. This is manifest in the fact
that alpha’s sampling standard deviation drops from 10 to 6 basis points per month when the
average same-month return is removed from the optimal characteristic set.
Table IA-20 shows that the γ = 5, singleton mean same-month return portfolio’s mean alpha
is 78 basis points per month [57.15 , 101.72] . The γ = 10 singleton residual standard deviation
17
portfolio has a mean alpha of 29 basis points per month [21 , 37].
This evidence provides another reminder of the danger of using alpha as a performance
measure, since the investor’s objective function is not linear. This fact is well known; for example
Leland (1999) and Ferson (2013) discuss the failings of alpha in evaluating equity portfolios.
Broadie, Chernov, and Johannes (2009) provide a reminder in the context of option returns.
6. Return Distributions and Moments
Figures 7 and 8 show the return distributions for four of the optimal portfolios–each contrasted
with the return distribution of the investor’s preferred benchmark.10 Table 4 shows sampling
distributions of portfolio moments for the benchmark portfolios and the nine optimal portfolios.
Tables IA-31–IA-44 provide this information for all 41 portfolios using each of the 14 gamma
values, respectively. Figure 7 shows that the risk tolerance of the gamma 2 investor generates
an optimal portfolio with a much greater scale than the equally-weighted index. The mean (95%
sampling band) of this optimal portfolio’s mean return is 549 ([465 , 645]) basis points per month.
The analogous moments for the equally-weighted benchmark are: 133 ([131 , 135]) basis points
per month. The Sharpe ratio shows that whereas the standard deviation is also larger than
the benchmark’s, the increase in the second moment is proportionately less. The Sharpe ratios
reported in these tables are annualized (i.e., the monthly numbers are multiplied by√
12). In
addition to mean, standard deviation, and Sharpe ratio, the tables provide bootstrap properties
of the return median, interquartile range, minimum return, and robust measures of skewness
(K3) and kurtosis (K4):
K3 =r+.95 − r
−.05
r+.5 − r−.5
− 2.63 (3)
and
K4 =r.95 − r.05
r.75 − r.25− 2.90 (4)
Where: r+.95 is the mean of the highest 5% of returns, r−.05 is the mean of the smallest 5% of
returns, r+.5 is the mean of the top half of returns, and r−.5 is the mean of the bottom half of
returns; and rx is the observation corresponding to the x%ile of the return data.11
Whereas Figure 7 shows that the return distribution of the optimal portfolio for gamma
2 investor is very different from that of the equally-weighted benchmark, it is neither more
skewed nor leptokurtic than this benchmark. The optimal portfolios for all more risk-averse10The figures aggregate the 492 months (in the out-of-sample period) over the 10,000 bootstrap draws, so that
the plotted empirical distributions have 4,920,000 observations.11The measures of skewness and kurtosis are recommended and discussed by Kim and White (2003).
18
investors are significantly more right-skewed than the benchmark. Tables IA-31 – IA-44 show
that some portfolios have significantly higher skews than the optimal one–using the same γ.
For example when γ = 3 is used to generate optimal portfolios the maximal skew is obtained
by conditioning on the book-to-market ratio, mean same-month returns, and last-year same-
month return. This portfolio’s median sampling skewness measure (95% sampling band) is
1.00 ([0.87 , 1.14])–significantly higher than the skewness measure of the returns on the optimal
portfolio for the gamma 2 investor: 0.44 ([0.31 , 0.57]). The portfolio with higher skew also has
fatter tails. The kurtosis median sampling kurtosis measure (95% sampling band) for the higher
skew portfolio is 1.29 ([0.85 , 1.80]), whereas that for the gamma 2 investor’s optimal portfolio
is 0.51 ([0.15 , 0.90]). The gamma 2 investor is the only one of the nine investors whose optimal
portfolio does not exhibit significantly more (positive) skewness than the preferred benchmark.
Table IA-32 shows that when used in isolation with γ = 3, momentum, book-to-market ratio,
residual standard deviation, and same-month return produce optimal portfolios that are more
positively skewed than the benchmark returns. Size, and beta do not.
The upper panel of Figure 8 shows the return distribution of the optimal portfolio for
the gamma 4 investor. The distribution is significantly more skewed and leptokurtic than the
benchmark–both facts are evident in this figure. The mean return of the most risk-averse in-
vestors’ optimal portfolio is 74 basis points higher (per month) than that of the value-weighted
benchmark. The standard deviation is not significantly higher than that of the benchmark.
Furthermore, the with a 95%ile sampling band of ([4.37 , 5.11]) (basis points per month), this
portfolio’s interquartile range is significantly lower than that of the benchmark ([6.03 , 6.33]).
Especially since these portfolios are more leptokurtic than the normal distribution the standard
deviation may give a distorted sense of the distribution’s scale. The interquartile range is a
nonparametric measure of scale. The lower panel of Figure 8 shows this portfolio along with the
value-weighted benchmark.
Table IA-34 shows that the γ = 5, singleton average same-month return optimal portfolio
has a significantly higher Sharpe ratio than that of the equally-weighted benchmark; its 95%
sampling band is ([0.67 , 0.81]) (the 97.5%ile of the equally-weighted benchmark’s Sharpe ratio
is 0.65). Both the portfolio mean return ([1.64 , 2.08]) and interquartile range ([6.42 , 7.69]) are
significantly higher than those of the benchmark. The use of same-month return to weight stocks
creates a portfolio that is significantly more positively skewed than the benchmark. It is also
more leptokurtic. This explains why the same-month return can be used in isolation by the most
risk-averse investors to improve utility relative to the equally-weighted benchmark. The variance
is lowered by reduced by lowered exposure to SMB and HML. This portfolio is far from optimal
for these risk-tolerant investors for this same fact. In contrast, the optimal portfolios for these
19
investors (Table 3) have lowered exposure to the market and increased exposure to SMB and
HML, relative to the equally-weighted benchmark. In addition they have significant exposure to
the momentum factor, which can only be achieved when momentum is included in the available
set of characteristics.
Table IA-40 that the γ = 11, singleton residual standard deviation has a significantly higher
Sharpe ratio than the value-weighted benchmark. This is primarily because the portfolio has a
lower standard deviation than the benchmark, as these portfolios’ mean returns are not statis-
tically different. Not only is this portfolio’s standard deviation lower than the value-weighted
benchmark’s, the interquartile range is proportionally much lower (with 95% band: [4.07 , 4.56]
compared to the value-weighted benchmark [5.20 , 5.59]). This is because this portfolio has sig-
nificantly higher kurtosis than the benchmark. Its skewness is not significantly different from
that of the value-weighted benchmark.
The optimal portfolio for the gamma 6 investor is constructed using γ = 11 as well, however
this portfolio has significantly higher mean and standard deviation than the benchmark. This
highlights another aspect of the complementarity between the characteristics. Midlevel risk-
averse investors optimally use the residual standard deviation to reduce portfolio variance, even
though they tolerate a higher variance than the market benchmark. The other characteristics,
especially the same-month return and momentum work to increase the expected return.
With γ = 9 Table IA-38 shows that using residual variance in isolation yields an optimal
portfolio with significantly higher mean return than using beta in isolation: [1.10 , 1.25] versus
[0.96 , 1.07]. Table IA-24 shows that these two portfolios have similar loadings on the Fama,
French, Carhart factors. The difference in mean returns is due entirely to alpha–using residual
variance in isolation produces a significantly higher alpha: 29 versus 13 basis points per month.
7. Monthly seasonal patterns
Since the average same-month return enters into the optimal characteristic set for all but the
most risk-averse investors, we turn to the question of how optimal portfolios vary across the 12
months of the year. Referring to the Fama, French, Carhart regressions, we examine the extent
to which there are timing biases in alpha that result from not conditioning on the month. To
this end, we compare the sampling distribution of the (unconditional) alpha in Tables IA-17 –
IA-30 with the (conditional) alpha from the 12 regressions that use only the 41 observations
from one month (e.g., all 41 Januaries, etc.). We follow Boguth, Carlson, Fisher, and Simutin
(2011) in defining the volatility timing bias which reflects correlation between the monthly factor
loading and the monthly factor variance; and risk-premium timing bias which reflects correlation
between the monthly factor loading and the monthly factor expected return.
20
In particular, define buj to be the unconditional loading of the portfolio returns on factor j
(estimated using the 492 out-of-sample months). Let bm,j be the loading of the portfolio return
in month m on fj,m, the return on factor j in month m, and bj be 112
12∑m=1
bm,j . The volatility
timing bias associated with factor j is then: fuj (bj − buj ), where fuj is the unconditional mean of
the return on factor j (over the 492 out-of-sample months). Defining f j,m as the mean return
on factor fj in month m, the total bias in α attributable to factor j is: 112
12∑m=1
bm,jf j,m − buj · f
uj .
The α− bias attributable to timing the risk premium is then defined as the total bias minus the
volatility timing bias.
We introduce alpha as that amount of the mean portfolio return that is orthogonal to the
Fama, French, Carhart factors, and do not suggest that it is devoid of risk. Indeed, since portfolio
alpha declines monotonically in γ there is no reason to identify it as a “free lunch.” Therefore we
use these biases simply as a metric to measure the importance of varying exposure to the Fama,
French, Carhart factors across the 12 months of the year.
For this decomposition to be meaningful, we need significant differences across the 12 months
in factor means and variances. Panel A of Table 5 provides the unconditional factor means and
standard errors over the 41 years in the out-of-sample period (1975 – 2015), by month of the year.
All four factors exhibit monthly seasonal patterns in both mean returns and standard deviations.
For example, the highest return on the market is in November (168 basis points) and the lowest
is in September (-84 basis points) – a statistically significant difference. The return on SMB in
January (141 basis points) is significantly higher than it is in October (-128 basis points), April
(-18 basis points), July (-66 basis points), and August (-13 basis points). The standard deviation
of momentum returns is more than twice as large in April as it is in August.
Tables IA-45 – IA-58 show the bootstrap sampling distributions for the volatility-, risk-
premium-, and total timing biases in alpha for the optimal portfolios selected using all 41 models,
for each of the 14 γ values, respectively. Panels B - H of Table 5 cull from these tables the optimal
portfolios for the 9 investors, respectively. Another reason to examine timing in the metric of the
alpha timing biases is that conceptually it can explain the disconnect between (out-of-sample)
alpha and expected utility.
The largest bias in Table IA-46, where γ = 3, is on the portfolio that conditions on momen-
tum, book-to-market, log size, and average same-month return. As reported in Table IA-18, the
average alpha on this portfolio is 154 basis points per month. This table shows that over half of
this alpha is due to non-constant loadings across the 12 months. With this set of characteristics
the portfolio invests more in the momentum factor in months when this factor has a higher risk
premium. This timing bias on momentum accounts for 21 of the 88 basis point bias. The two
largest components of the bias are volatility timing on SMB and HML. In all volatility timing
21
accounts for 69% of the total timing bias. SMB volatility timing accounts for 31 of the 88 basis
point bias, and HML volatility timing accounts for 25 basis points.
The timing biases in the nine optimal portfolios reported in Table 5 are much smaller. Of
these, the largest is also using γ = 3, which is optimal for the gamma 2 investor. In this case
varying factor loadings across the 12 months of the year means that the portfolio has significantly
less exposure to the market and to HML in those months when the market risk premium is higher
and the return on HML is higher. The portfolio has significantly more exposure to SMB and
MOM in those months when the returns on these two factors are higher. This portfolio also has
significantly more exposure to the market and SMB in those months when the returns on these
factors are more volatile, and significantly less exposure to MOM in the months when this factor
is more volatile.
Studies examining the ability of same-month return to produce alpha have not explored the
possibility that some of this alpha may be spurious, since the means and variances of the four
factors exhibit significant month-by-month variation.12 Table IA-49 shows the timing biases of
the optimal portfolio obtained using γ = 6. The portfolio that is formed by conditioning only
on the two same-month return characteristics has a mean monthly alpha of 63 basis points per
month–close to the 68 basis points reported in Heston and Sadka (2008).13 The table shows that
this alpha includes a 45% bias. Most of this bias (90% of the total timing bias) is the result
of increased exposure to the three Fama and French factors in months when they have higher
volatility. There is significantly positive volatility timing bias on the market risk premium, SMB,
and HML. This portfolio also significantly positively times the risk premium of momentum and
SMB– loading more heavily on these factors in months when they have higher expected returns.
It also negatively times the market and momentum–loading more heavily on these factors in
months when their expected returns are lower. While all four of these risk-premium timing
biases are statistically significant, their magnitudes are small relative to the volatility timing
biases. This is entirely consistent with Keloharju, Linnainmaa, and Nyberg.
Table IA-46 shows that conditioning on momentum by itself, using γ = 3, results in a portfolio
whose unconditional factor loadings significantly understate exposure to the volatility in SMB.
This results in overstating alpha by 8 basis points per month. The converse of this is also shown
in this table: a portfolio formed using γ = 3 and conditioning only on size has significantly lower
12This is a motivation of Keloharju, Linnainmaa, and Nyberg (2016). Indeed they note that a portfolio of stocksranked by January returns is likely to look like SMB in January. Their point is that same-month returns proxyfor systematic factor exposure. They posit that these factors are latent, and many may be relatively small. Herewe measure the extent to which this time-variation in factor loadings applies to the four Fama, French, Carhartfactors.
13See Heston and Sadka (2008) Table 3, p. 426. A portfolio that is long the top 10% same-month returns inyears 2 – 5 and short the bottom 10% same-month returns in years 2 – 5 earns a Fama and French alpha of 68basis points per month (with a 3.7 t−statistic).
22
exposure to the momentum factor in those months when this factor is less volatile. The table also
shows that in isolation, beta generates an optimal portfolio that successfully times the volatility
in the market, SMB, and HML. The portfolio’s loadings on all three of these factors are lower in
those months when they are more volatile.
Table IA-46 shows that risk-tolerant investors using average same-month return in isolation
produces a portfolio that has higher exposures to: the market factor, SMB, and HML in the
months when those factors have higher variances. In contrast, Table IA-52 shows that midlevel
risk-averse investors conditioning only residual standard deviation reduce portfolio variance by
loading more heavily on SMB and HML in those months when these factor variances are low.
Table IA-52 also shows that conditioning only on beta has a similar effect.
Table IA-57 shows that the most risk-averse loss functions in our analysis use (γ = 16, and)
the characteristics: momentum, size, and residual standard deviation to reduce the portfolio’s
exposure to SMB, HML, and MOM, the momentum factor, in those months when their variances
are high. This results in understating the portfolio alpha by 15 basis points per month on average.
Although momentum is the only “dynamic” characteristic among these three–used optimally by
the gamma 8, 9, and 10 investors–this table suggests that momentum in isolation does not
successfully time the volatility exposure to any of the four factors. Conditioning on the residual
standard deviation and/or beta, which are both persistent by construction, successfully times
the exposures to SMB and HML, in the sense that factor exposure is lower in the months of the
year when the factor is more volatile.
8. Conclusion
This paper complements studies that examine the usefulness of observable stock character-
istics to predict returns in the cross-section. To what extent is this documented predictability
useful for risk-averse investors? The first step in answering this question is addressing estimation
risk. Estimation risk has plagued portfolio selection algorithms over the years, manifest in the
popularity of norms such as equal-weighting (as emphasized by DeMiguel, Garlappi, and Uppal
2009). Although the Brandt, Santa-Clara, and Valkanov (2009) algorithm estimates a small
number of coefficients it also suffers from estimation risk. We address that risk by inflating the
investor’s risk aversion coefficient to select the portfolios. For all the investors we consider the
optimal portfolio represents a large and statistically significant improvement in expected utility.
Momentum, log size, and the market model residual standard deviation enter the optimal
set of characteristics of all investors. As investors become more risk-tolerant lagged same-month
return is added to the optimal characteristic set. Increasing risk-tolerance further, makes the
market model beta a useful characteristic. The book-to-market ratio never enters the optimal
23
characteristic set. The information in this characteristic is spanned by the other characteristics
and since all of our analysis is out-of-sample parsimony is rewarded.
All of the optimal portfolios’ loading on the market factor is significantly less than one,
and are insensitive to investor risk-aversion. The portfolios’ exposure to the size factor (SMB),
value factor (HML) and momentum factor (MOM) all decrease in risk-aversion. All portfolios
have a significant four-factor alpha which also decreases monotonically in risk-aversion. With
the exception of the most risk-averse investor’s, these optimal portfolios’ return distributions
are significantly more positively skewed and have fatter tails than market index portfolios. The
Sharpe ratios of the optimal portfolios are significantly larger than the market benchmarks–
roughly twice as large. The efficacy of measurable characteristic-based investing is not diminished
(and perhaps it is even expanded) by taking into consideration risk aversion and portfolio return
variance, skewness, and kurtosis.
While Brandt, Santa-Clara, and Valkanov (2009) is structured as a normative algorithm we
use it to test and measure the relationships between characteristic and future portfolio returns
in our data. There are two reasons that limit the normative implications of this study. First,
all of our tests are out-of-sample in the sense that data used to evaluate portfolio properties is
different from the data estimate portfolio weights. However, we use the “out-of-sample” periods
to manage estimation risk (i.e., overfitting), which effectively brings it “in-sample.” Second, as
noted by Brandt, Santa-Clara, and Valkanov, we use data whose properties have already been
studied–informing our choice of eligible characteristics. Finally, we do not include a riskless asset
or other asset classes, whose presence might also mitigate estimation risk.
24
References
Barroso, Pedro and Pedro Santa-Clara, 2015, Momentum has its moments, Journal of Financial
Economics 116, 111–120.
Boguth, Oliver, Murray Carlson, Adlai Fisher, and Mikhail Simutin, 2011, Conditional risk and
performance evaluation: Volatility timing, overconditioning, and new estimates of momentum
alphas, Journal of Financial Economics 102, 363–389.
Brandt, Michael W., Pedro Santa-Clara, and Rossen Valkanov, 2009, Parametric portfolio policies:
Exploiting characteristics in the cross-section of equity returns, Review of Financial Studies 22,
3411–3447.
Broadie, Mark, Mikhail Chernov, and Michael Johannes, 2009, Understanding index option returns,
Review of Financial Studies 22, 4493–4529.
DeMiguel, Victor , Lorenzo Garlappi, and Raman Uppal, 2009, Optimal versus naive diversification:
How inefficient is the 1/N portfolio strategy?, Review of Financial Studies 22, 1915–1953.
Ferson, Wayne, 2013, Ruminations on investment performance measurement, European Financial
Management 19, 4–13.
Frazzini, Andrea and Lasse Heje Pedersen, 2013, Betting against beta, Journal of Financial Economics
111, 1–25.
Heston, Steve L. and Ronnie Sadka, 2008, Seasonality in the cross-section of stock returns, Journal
of Financial Economics 87, 418–445.
Keloharju, Matti, Juhani T. Linnainmaa, and Peter Nyberg, 2016, Return seasonalities, Journal of
Finance 71, 1557–1589.
Kim, Tae-Hwan and Halbert White, 2003, On more robust estimation of skewness and kurtosis:
Simulation and application to the S&P 500 Index, Working Paper, University of California, San
Diego.
Kogan, Leonid and Dimitris Papanikolaou, 2013, Firm characteristics and stock returns: The role of
investment-specific shocks, Review of Financial Studies 26, 2718–2759.
25
Leland, Hayne, 1999, Beyond mean-variance: Performance measurement in a nonsymmetrical world,
Financial Analysts Journal, 27–36.
Lewellen, Jonathan, 2013, The cross section of expected stock returns, Critical Finance Review 4,
1–44.
Lewellen, Jonathan, Stefan Nagel, and Jay Shanken, 2010, A skeptical appraisal of asset pricing tests,
Journal of Financial Economics 96, 175–194.
McLean, R. David and Jeffrey Pontiff, 2016, Does academic research destroy stock return predictabil-
ity? Journal of Finance 71, 5–31.
26
0
500
1000
1500
2000
2500 Jan-60
Sep-73
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Oct-14
Fig
ure
1.N
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23
45
6T
heta
Coe
ffici
ent o
n m
omen
tum
This panel shows the bootstrap distributions for the coefficient onmomentum for the case when momentum is the only characteristic.The box and whiskers show the 95%ile range (whiskers), the interquartilerange (box), and median (bar inside box) for the coefficient in each year. The sample estimate is shown as a red X.
x
x
x
x xx
xx
x
xx x x x x
x xx x x x x x x
x x xx
xx x x x x x x x
x x x x x x
45
67
Year 1974 − 2014 Using gamma = 3
The
ta C
oeffi
cien
t on
mom
entu
m
This panel shows the bootstrap distributions for the coefficient on momentumwhen the characteristics are: momentum, size, beta, residual standarddeviation, and average same−month return.
The box and whiskers show the 95%ile(whiskers), the interquartile range (box), and median (bar inside box) for thecoefficient in each year.The sample estimate is shown as a red X.
xx x
xx x
xx
x x x x x x x x x x x x xx x x
xx
x
x xx x x x x x
x x x x x x
Figure 2. Annual coefficient on stocks’ momentum This graph depicts properties ofthe sampling distributions of the coefficient on (standardized and normalized) momentum foreach year in the out-of-sample period (1975 – 2015). Both panels are for the case where γ (thecoefficient of relative risk-aversion) is 3, and the updating protocol is used. This is the θ coefficientthat governs the effect of momentum on the weight placed on each stock in the optimal portfolioin the following year. The set of characteristics used in the lower panel generates the optimalportfolio for the gamma 2 investor.
−4
−3
−2
−1
0T
heta
Coe
ffici
ent o
n si
ze
This panel shows the bootstrap distributions for the coefficient on size for the case when size is the onlycharacteristic. The box and whiskers show the 95%ile range (whiskers), the interquartile range (box),and median (bar inside box) for the coefficient in each year. The sample estimate is shown as a red X.x
x
x
x
x
x xx x
xx
x x xx
x xx
xx x x x x x x
x x x
x xx x x x
x x x x x x x x
−14
−12
−10
−8
Year 1974 − 2014 Using gamma = 3
The
ta C
oeffi
cien
t on
size
This panel shows the bootstrap distributionsfor the coefficient on size when the characteristicsare: momentum, size, beta, residual standarddeviation, and average same−month returns.The box and whiskers show the 95%ile range(whiskers), the interquartile range (box),and median (bar inside box) for the coefficientin each year.
The sample estimate is shown as a red X.
x x
x
xx
x
x
x xx x x x
x xx
x x x x xx x x
xx
x x x x x x x
x xx x x x x
x
Figure 3. Annual coefficient on stocks’ log size This graph depicts properties of thesampling distributions of the coefficient on (standardized and normalized) log size for each yearin the out-of-sample period (1975 – 2015). Both panels are for the case where γ (the coefficientof relative risk-aversion) is 3, and the updating protocol is used. This is the θ coefficient thatgoverns the effect of log size on the weight placed on each stock in the optimal portfolio in thefollowing year. The set of characteristics used in the lower panel generates the optimal portfoliofor the gamma 2 investor.
−2.
5−
1.5
−0.
5T
heta
Coe
ffici
ent o
n be
ta
This panel shows the bootstrap distributions for the coefficient on beta for the case when beta is the only characteristic. The box and whiskers show the 95%ile range (whiskers),the interquartile range (box), and median (bar inside box) for the coefficient in each year.
The sample estimate is shown as a red X.
x
x
x
x
xx
xx
x
xx x
xx
x x x x xx
x x x x xx x
xx x
xx x x x x
xx x x x x x
−4
−2
02
46
8
Year 1974 − 2014 Using gamma = 3
The
ta C
oeffi
cien
t on
beta
This panel shows the bootstrap distributionsfor the coefficient on beta when the characteristicsare: momentum, size, beta, residual standarddeviation, and average same−month returns.The box and whiskers show the 95%ile range(whiskers), the interquartile range (box),and median (bar inside box) for the coefficientin each year.
The sample estimate is shown as a red X.
x x x x
x
xx
x x x x x x x x x xx
x x x x x xx
x x x xx x x x x x
x x x x x x
Figure 4. Annual coefficient on stocks’ beta This graph depicts properties of the samplingdistributions of the coefficient on (standardized and normalized) beta for each year in the out-of-sample period (1975 – 2015). Both panels are for the case where γ (the coefficient of relativerisk-aversion) is 3, and the updating protocol is used. This is the θ coefficient that governs theeffect of beta on the weight placed on each stock in the optimal portfolio in the following year.The set of characteristics used in the lower panel generates the optimal portfolio for the gamma2 investor.
−3.
0−
2.0
−1.
0T
heta
Coe
ffici
ent o
n si
gma
This panel shows the bootstrap distributions for the coefficient on residual standard deviation forthe case where it is the only characteristic. The box and whiskers show the 95%ile range(whiskers), the interquartile range (box), and median (bar inside box) for the coefficient in eachyear.
The sample estimate is shown as a red X.
x xx x xx
x
x
x
xx x
xx
xx x x x
x x x x x xx x
x
x xx
x x x x xx x x x x x x
−18
−14
−10
−6
−4
Year 1974 − 2014 Using gamma = 3
The
ta C
oeffi
cien
t on
sigm
a
This panel shows the bootstrap distributions for the coefficient on residual standard deviationwhen the characteristics are: momentum, size, beta, residual standard deviation, and averagesame−month returns. The box and whiskers show the 95%ile range (whiskers), the interquartile
range (box), and median (bar inside box) for the coefficient in each year.
The sample estimate is shown as a red X.
x x xx
x
xx x x x x x x x x x x
xx x x x x x x x x x x
x x x xx x
x x x x x x
Figure 5. Annual coefficient on stocks’ residual standard deviation This graph depictsproperties of the sampling distributions of the coefficient on (standardized and normalized) resid-ual standard deviation for each year in the out-of-sample period (1975 – 2015). Both panels arefor the case where γ (the coefficient of relative risk-aversion) is 3, and the updating protocol isused. This is the θ coefficient that governs the effect of residual standard deviation on the weightplaced on each stock in the optimal portfolio in the following year. The set of characteristicsused in the lower panel generates the optimal portfolio for the gamma 2 investor.
68
1012
The
ta C
oeffi
cien
t on
r−ba
r
This panel shows the bootstrap distributions for the coefficient on average same−month return forthe case where it is the only characteristic. The box and whiskers show the 95%ile range(whiskers), the interquartile range (box), and median (bar inside box) for the coefficient in eachyear.
The sample estimate is shown as a red X.
x xx x x xx
x
x
x
x x xx
x x xx
xx x x x x x
x
xx
x
x x x x x x x x x x x x x x
68
1012
14
Year 1974 − 2014 Using gamma = 3
The
ta C
oeffi
cien
t on
r−ba
r
This panel shows the bootstrap distributions for the coefficient on average same−month returnwhen the characteristics are: momentum, size, beta, residual standard deviation, and averagesame−month returns. The box and whiskers show the 95%ile range (whiskers), the interquartile
range (box), and median (bar insidebox) for the coefficient in each year.
The sample estimate is shown as a red X.
xx x x
xx
x
xx x x x
x x xx x x x x x x x x x x
x
x xx x x x
x x x x x x x x
Figure 6. Annual coefficient on stocks’ 5-year average same-month return This graphdepicts properties of the sampling distributions of the coefficient on (standardized and normal-ized) the 5-year average same-month return for each year in the out-of-sample period (1975 –2015). Both panels are for the case where γ (the coefficient of relative risk-aversion) is 3, and theupdating protocol is used. This is the θ coefficient that governs the effect of the 5-year averagesame-month return on the weight placed on each stock in the optimal portfolio in the followingyear. The set of characteristics used in the lower panel generates the optimal portfolio for thegamma 2 investor.
dens
ity
Portfolio
EWIOpt forGamma 2
−0.2 0.0 0.2returns
dens
ity
PortfolioOpt forGamma 7VWI
Figure 7. Densities of monthly returns on optimal portfolio and indices The panels inthis figure compare the density function of the monthly returns from an optimal portfolio withthe relevant benchmark portfolio.
dens
ity
Portfolio
EWIOpt forGamma 4
−0.2 0.0 0.2returns
dens
ity
PortfolioOpt forGamma 9VWI
Figure 8. Densities of monthly returns on optimal portfolio and indices The panels inthis figure compare the density function of the monthly returns from an optimal portfolio withthe relevant benchmark portfolio.
Tab
le1
Max
imin
cert
aint
yeq
uiva
lent
:ba
sis
poin
tspe
rm
onth
Por
tfol
ioB
oots
trap
Boo
tstr
apSa
mpl
eB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
/M
ean
Stan
dard
2.5%
ile25
%ile
50%
ile75
%ile
97.5
%ile
Cha
ract
eris
tics
Dev
iati
onG
amm
a2
inve
stor
EW
I:10
5.9
1.1
105.
910
3.6
105.
110
5.9
106.
610
8.1
VW
I:87
.82.
387
.983
.486
.387
.889
.492
.3U
sing
γ=
2M
,V
,S
140.
520
.814
9.9
98.7
128.
014
1.4
154.
117
8.6
M,
V,
S,σε
-376
0.3
4706
.037
74.1
-100
00.0
-100
00.0
-282
.5-3
.610
3.0
Usi
ngγ
=3
M,
S,β
,σε,rt−
12j
335.
810
6.8
376.
428
7.6
318.
433
6.2
354.
639
0.3
M,
V,
S,σε
134.
443
4.6
157.
531
.914
2.2
163.
417
9.4
203.
5U
sing
γ=
4M
,S,β
,σε,r t−
12j
320.
722
.935
0.0
277.
930
4.9
319.
833
5.7
367.
3M
,V
,S,σε
190.
815
.619
3.9
158.
918
1.6
191.
420
1.0
218.
9U
sing
γ=
5M
,S,β
,σε,r t−
12j
297.
720
.132
1.0
260.
028
3.8
297.
131
0.9
339.
1M
,V
,S,β
,σε,r t−
12,r t−
12j
298.
831
2.0
342.
424
7.5
291.
230
9.8
328.
436
5.5
Usi
ngγ
=6
M,
V,
S,β
,σε,r t−
12,r t−
12j
277.
918
.829
7.7
242.
526
5.2
277.
429
0.2
316.
9M
,V
,S,β
,σε,r t−
12,r t−
12j
291.
015
1.2
323.
024
4.0
277.
729
3.6
309.
934
2.0
Usi
ngγ
=7
M,
V,
S,β
,σε,r t−
12,r t−
12j
260.
017
.127
7.4
228.
324
8.3
259.
327
1.1
294.
8M
,V
,S,β
,σε,r t−
12,r t−
12j
277.
121
.630
2.6
236.
326
2.7
276.
929
1.1
320.
2U
sing
γ=
8M
,S,σε,r t−
12j
241.
413
.125
1.8
216.
623
2.4
241.
025
0.0
268.
1M
,V
,S,β
,σε,r t−
12,r t−
12j
261.
219
.628
3.9
224.
224
7.9
261.
327
4.3
300.
0U
sing
γ=
9M
,S,σε,r t−
12j
230.
412
.123
9.6
207.
722
2.1
230.
023
8.2
255.
5M
,V
,S,β
,σε,r t−
12,r t−
12j
247.
517
.926
7.5
214.
023
5.4
247.
125
9.4
283.
0
Tab
le1
Con
tinu
ed
Max
imin
cert
aint
yeq
uiva
lent
:ba
sis
poin
tspe
rm
onth
Por
tfol
ioB
oots
trap
Boo
tstr
apSa
mpl
eB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
/M
ean
Stan
dard
2.5%
ile25
%ile
50%
ile75
%ile
97.5
%ile
Cha
ract
eris
tics
Dev
iati
onG
amm
a2
inve
stor
,co
nti
nu
ed:
Usi
ngγ
=10
M,
S,σε,r t−
12j
220.
911
.622
9.3
199.
821
2.9
220.
522
8.5
244.
7M
,V
,S,β
,σε,r t−
12,r t−
12j
235.
016
.425
3.0
203.
722
3.7
234.
724
6.0
267.
8U
sing
γ=
11M
,S,σε,r t−
12j
212.
510
.822
0.3
192.
520
5.2
212.
021
9.6
235.
0M
,V
,S,β
,σε,r t−
12,r t−
12j
224.
415
.424
0.3
195.
521
3.7
224.
123
4.7
255.
8U
sing
γ=
12M
,S,σε,r t−
12j
205.
710
.421
2.5
186.
519
8.4
205.
421
2.4
226.
7M
,V
,S,β
,σε,r t−
12,r t−
12j
214.
414
.322
9.1
187.
620
4.7
214.
222
3.6
243.
5U
sing
γ=
13M
,S,σε,r t−
12j
199.
49.
820
5.7
181.
119
2.5
199.
020
5.9
219.
3M
,V
,S,β
,σε,r t−
12,r t−
12j
206.
113
.621
9.1
180.
319
6.7
205.
721
5.0
233.
7U
sing
γ=
16M
,S,σε,r t−
12j
184.
58.
918
9.4
167.
617
8.4
184.
319
0.3
202.
8M
,S,σε,r t−
12j
182.
89.
818
8.8
163.
517
6.2
182.
718
9.3
202.
5U
sing
γ=
22M
,S,σε,r t−
12j
164.
68.
416
7.5
148.
815
8.9
164.
417
0.1
181.
5M
,S,σε,r t−
12j
161.
69.
716
5.4
143.
115
5.1
161.
416
7.9
180.
7
Gam
ma
3in
vest
or:
EW
I:91
.71.
191
.889
.490
.991
.792
.593
.9V
WI:
77.6
2.3
77.9
73.1
76.1
77.7
79.2
82.1
Usi
ngγ
=3
M,
S,β
,σε,r t−
12j
209.
111
1.4
256.
013
6.4
191.
621
3.1
233.
326
9.3
M,
V,
S,σε
-61.
954
9.0
-13.
2-6
73.7
-41.
528
.066
.710
8.6
Usi
ngγ
=4
M,
S,β
,σε,r t−
12j
248.
820
.527
9.8
208.
923
5.2
248.
326
2.2
290.
0M
,V
,S,σε
122.
133
.712
1.5
45.8
111.
412
8.5
141.
016
1.0
Tab
le1
Con
tinu
ed
Max
imin
cert
aint
yeq
uiva
lent
:ba
sis
poin
tspe
rm
onth
Por
tfol
ioB
oots
trap
Boo
tstr
apSa
mpl
eB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
/M
ean
Stan
dard
2.5%
ile25
%ile
50%
ile75
%ile
97.5
%ile
Cha
ract
eris
tics
Dev
iati
onG
amm
a3
inve
stor
,co
nti
nu
ed:
Usi
ngγ
=5
M,
S,β
,σε,rt−
12j
249.
117
.627
3.0
215.
523
7.1
248.
926
0.9
284.
4M
,V
,S,σε
151.
314
.215
2.3
119.
714
3.6
152.
516
0.7
175.
4U
sing
γ=
6M
,S,β
,σε,r t−
12j
240.
016
.025
9.9
209.
422
9.1
239.
625
0.5
272.
9M
,V
,S,β
,σε,r t−
12,r t−
12j
228.
818
6.6
259.
715
9.2
220.
923
7.7
253.
228
2.8
Usi
ngγ
=7
M,
S,β
,σε,r t−
12j
229.
214
.524
6.2
202.
321
9.2
228.
923
8.7
258.
8M
,V
,S,β
,σε,r t−
12,r t−
12j
232.
526
.625
4.6
182.
721
9.5
234.
324
8.1
274.
7U
sing
γ=
8M
,S,σε,r t−
12j
217.
011
.922
7.2
194.
420
8.8
216.
722
4.9
240.
9M
,V
,S,β
,σε,r t−
12,r t−
12j
225.
025
.924
5.2
181.
921
3.0
226.
523
9.0
263.
0U
sing
γ=
9M
,S,σε,r t−
12j
209.
311
.121
8.4
188.
520
1.6
209.
021
6.4
232.
3M
,V
,S,β
,σε,r t−
12,r t−
12j
217.
122
.423
4.7
179.
620
5.7
217.
522
9.7
252.
1U
sing
γ=
10M
,S,σε,r t−
12j
202.
210
.721
0.4
182.
419
4.8
201.
820
9.2
224.
3M
,V
,S,β
,σε,r t−
12,r t−
12j
208.
617
.122
4.3
174.
719
7.7
208.
922
0.1
241.
1U
sing
γ=
11M
,S,σε,r t−
12j
195.
610
.120
3.2
176.
918
8.7
195.
120
2.3
216.
4M
,V
,S,β
,σε,r t−
12,r t−
12j
200.
816
.021
4.6
170.
319
0.4
200.
921
1.3
231.
6U
sing
γ=
12M
,S,σε,r t−
12j
190.
09.
719
6.8
171.
918
3.1
189.
819
6.3
209.
7M
,V
,S,β
,σε,r t−
12,r t−
12j
192.
814
.820
5.5
163.
918
3.0
192.
720
2.4
221.
8U
sing
γ=
13M
,S,σε,r t−
12j
184.
79.
319
1.0
167.
317
8.3
184.
319
0.9
203.
5M
,V
,S,β
,σε,r t−
12,r t−
12j
185.
914
.219
7.1
158.
317
6.5
185.
919
5.1
213.
5
Tab
le1
Con
tinu
ed
Max
imin
cert
aint
yeq
uiva
lent
:ba
sis
poin
tspe
rm
onth
Por
tfol
ioB
oots
trap
Boo
tstr
apSa
mpl
eB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
/M
ean
Stan
dard
2.5%
ile25
%ile
50%
ile75
%ile
97.5
%ile
Cha
ract
eris
tics
Dev
iati
onG
amm
a3
inve
stor
,co
nti
nu
ed:
Usi
ngγ
=16
M,
S,σε,r t−
12j
171.
68.
617
6.5
155.
016
5.8
171.
417
7.2
189.
2M
,S,σε,r t−
12j
167.
010
.517
2.5
145.
716
0.1
167.
117
3.9
187.
3U
sing
γ=
22M
,S,σε,r t−
12j
153.
18.
315
6.2
137.
514
7.5
153.
015
8.7
169.
7M
,S,σε,r t−
12j
146.
910
.615
0.6
125.
513
9.9
147.
015
4.0
167.
4
Gam
ma
4in
vest
or:
EW
I:76
.91.
277
.074
.676
.176
.977
.779
.2V
WI:
67.2
2.3
67.6
62.5
65.6
67.2
68.7
71.7
Usi
ngγ
=4
V,
S,σε
101.
18.
210
4.2
84.6
95.8
101.
210
6.6
116.
8M
,V
,S,σε
28.6
94.8
24.9
-166
.812
.750
.573
.410
2.0
Usi
ngγ
=5
M,
S,β
,σε,r t−
12j
196.
718
.622
2.0
159.
118
5.3
197.
120
9.0
230.
6M
,V
,S,σε
101.
225
.998
.539
.791
.110
6.0
117.
313
4.0
Usi
ngγ
=6
M,
S,σε,r t−
12j
192.
914
.420
6.5
164.
118
4.0
193.
120
2.2
219.
8M
,V
,S,σε
124.
613
.912
4.0
91.9
117.
412
6.2
133.
914
6.5
Usi
ngγ
=7
M,
S,β
,σε,rt−
12j
198.
813
.721
6.0
172.
718
9.5
198.
820
7.8
226.
2M
,S,σε
134.
110
.413
4.4
111.
212
8.2
134.
814
1.0
152.
1U
sing
γ=
8M
,S,σε,r t−
12j
191.
211
.420
1.2
169.
218
3.6
191.
119
8.7
213.
8M
,S,σε
137.
78.
513
9.1
120.
013
2.5
138.
014
3.4
153.
5
Tab
le1
Con
tinu
ed
Max
imin
cert
aint
yeq
uiva
lent
:ba
sis
poin
tspe
rm
onth
Por
tfol
ioB
oots
trap
Boo
tstr
apSa
mpl
eB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
/M
ean
Stan
dard
2.5%
ile25
%ile
50%
ile75
%ile
97.5
%ile
Cha
ract
eris
tics
Dev
iati
on
Gam
ma
4in
vest
or,
conti
nu
ed:
Usi
ngγ
=9
M,
S,σε,r t−
12j
187.
110
.619
6.0
167.
017
9.9
187.
019
4.0
208.
5M
,V
,S,β
,σε,r t−
12,r t−
12j
183.
648
.919
9.9
128.
817
3.6
187.
119
9.4
221.
6U
sing
γ=
10M
,S,σε,r t−
12j
182.
510
.219
0.6
163.
217
5.6
182.
318
9.2
203.
4M
,V
,S,β
,σε,r t−
12,r t−
12j
180.
022
.519
3.9
134.
216
9.4
182.
219
3.6
214.
4U
sing
γ=
11M
,S,σε,r t−
12j
177.
89.
718
5.3
159.
417
1.2
177.
518
4.2
197.
5M
,V
,S,β
,σε,r t−
12,r t−
12j
175.
320
.518
7.2
135.
016
5.0
176.
518
7.5
207.
8U
sing
γ=
12M
,S,σε,r t−
12j
173.
49.
418
0.2
155.
416
6.9
173.
317
9.6
192.
4M
,S,σε,r t−
12j
164.
314
.717
0.5
133.
915
6.3
165.
417
3.7
189.
0U
sing
γ=
13M
,S,σε,r t−
12j
169.
29.
117
5.4
152.
116
3.1
169.
017
5.3
187.
7M
,S,σε,r t−
12j
160.
813
.616
6.4
131.
615
3.1
161.
816
9.5
184.
6U
sing
γ=
16M
,S,σε,r t−
12j
158.
18.
616
3.0
141.
315
2.4
158.
016
3.7
175.
1M
,S,σε,r t−
12j
149.
612
.615
4.5
122.
414
2.3
150.
515
8.0
171.
5U
sing
γ=
22M
,S,σε,r t−
12j
140.
98.
514
4.1
124.
613
5.3
140.
814
6.6
157.
8M
,S,σε,r t−
12j
130.
612
.813
4.1
103.
812
2.8
131.
313
9.2
153.
4
Tab
le1
Con
tinu
ed
Max
imin
cert
aint
yeq
uiva
lent
:ba
sis
poin
tspe
rm
onth
Por
tfol
ioB
oots
trap
Boo
tstr
apSa
mpl
eB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
/M
ean
Stan
dard
2.5%
ile25
%ile
50%
ile75
%ile
97.5
%ile
Cha
ract
eris
tics
Dev
iati
on
Gam
ma
5in
vest
or:
EW
I:61
.41.
261
.659
.060
.661
.462
.263
.8V
WI:
56.4
2.4
56.9
51.6
54.7
56.4
58.0
61.1
Usi
ngγ
=5
V,
S,σε
91.1
7.5
94.3
75.9
86.3
91.4
96.1
105.
4M
,V
,S,σε
38.5
52.8
31.2
-87.
023
.151
.069
.292
.2U
sing
γ=
6M
,S,β
,σε,r t−
12j
160.
317
.518
1.7
123.
614
9.9
161.
217
1.8
192.
2M
,V
,S,σε
84.4
23.0
80.5
25.6
74.9
89.1
99.4
114.
5U
sing
γ=
7M
,S,σε,r t−
12j
160.
514
.317
2.1
130.
715
2.3
161.
116
9.9
186.
0M
,V
,S,σε
102.
915
.110
1.6
68.5
95.4
105.
211
2.8
125.
1U
sing
γ=
8M
,S,β
,σε,r t−
12j
166.
513
.318
1.8
140.
215
8.1
166.
817
5.2
192.
0M
,V
,S,σε
111.
810
.811
1.3
87.1
106.
011
2.8
118.
812
9.9
Usi
ngγ
=9
M,
S,σε,rt−
12j
163.
511
.217
2.3
141.
115
6.3
163.
717
0.9
184.
6M
,V
,S,σε
115.
59.
011
5.6
96.4
110.
211
6.0
121.
513
1.5
Usi
ngγ
=10
M,
S,σε,r t−
12j
161.
610
.516
9.6
140.
515
4.8
161.
616
8.6
182.
1M
,S,σε
118.
47.
811
9.6
102.
511
3.5
118.
612
3.6
132.
9U
sing
γ=
11M
,S,σε,r t−
12j
158.
910
.016
6.2
139.
415
2.4
158.
916
5.5
178.
2M
,S,σε
118.
47.
111
9.8
104.
111
3.8
118.
612
3.2
132.
0U
sing
γ=
12M
,S,σε,r t−
12j
155.
99.
616
2.6
137.
014
9.5
156.
016
2.3
174.
6M
,S,σε
117.
46.
811
9.0
103.
811
2.9
117.
412
2.0
130.
6
Tab
le1
Con
tinu
ed
Max
imin
cert
aint
yeq
uiva
lent
:ba
sis
poin
tspe
rm
onth
Por
tfol
ioB
oots
trap
Boo
tstr
apSa
mpl
eB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
/M
ean
Stan
dard
2.5%
ile25
%ile
50%
ile75
%ile
97.5
%ile
Cha
ract
eris
tics
Dev
iati
on
Gam
ma
5in
vest
or,
conti
nu
ed:
Usi
ngγ
=13
M,
S,σε,r t−
12j
152.
89.
315
8.9
134.
814
6.7
152.
815
9.1
171.
4M
,S,σε
115.
76.
711
7.4
102.
211
1.2
115.
712
0.2
129.
0U
sing
γ=
16M
,S,σε,r t−
12j
143.
68.
914
8.5
125.
513
8.0
143.
714
9.5
161.
1M
,S,σε
109.
16.
711
1.0
95.9
104.
610
9.1
113.
712
2.3
Usi
ngγ
=22
M,
S,σε,r t−
12j
127.
89.
113
1.0
109.
512
1.8
127.
813
4.0
145.
6M
,S,σε
94.7
7.8
96.6
79.2
89.6
94.7
99.9
109.
7
Gam
ma
6in
vest
or:
EW
I:45
.11.
345
.342
.644
.245
.146
.047
.6V
WI:
45.1
2.5
45.9
40.3
43.5
45.1
46.8
50.0
Usi
ngγ
=6
V,
S,σε
81.4
7.4
84.5
65.8
76.8
81.7
86.4
95.0
M,
V,
S,σε
36.5
40.1
28.1
-67.
422
.346
.261
.982
.2U
sing
γ=
7M
,S,β
,σε,r t−
12j
166.
414
.715
0.3
136.
415
7.4
166.
817
6.1
193.
3M
,V
,S,σε
68.4
24.2
64.3
11.6
58.6
73.2
83.7
98.5
Usi
ngγ
=8
M,
S,β
,σε,r t−
12j
137.
615
.815
3.6
103.
312
8.8
138.
914
7.9
165.
1M
,V
,S,σε
84.6
15.5
81.9
47.0
77.7
87.1
94.8
106.
8U
sing
γ=
9M
,S,β
,σε,r t−
12j
139.
014
.515
2.9
109.
213
1.0
139.
814
8.1
164.
0M
,S,σε
93.8
12.0
92.3
65.8
87.9
95.5
101.
711
1.9
Usi
ngγ
=10
M,
S,σε,r t−
12j
139.
212
.214
7.0
113.
113
2.2
139.
914
7.3
160.
8M
,S,σε
98.0
9.7
97.8
76.8
92.7
98.9
104.
511
4.5
Tab
le1
Con
tinu
ed
Max
imin
cert
aint
yeq
uiva
lent
:ba
sis
poin
tspe
rm
onth
Por
tfol
ioB
oots
trap
Boo
tstr
apSa
mpl
eB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
/M
ean
Stan
dard
2.5%
ile25
%ile
50%
ile75
%ile
97.5
%ile
Cha
ract
eris
tics
Dev
iati
on
Gam
ma
6in
vest
or,
conti
nu
ed:
Usi
ngγ
=11
M,
S,σε,rt−
12j
138.
611
.414
5.8
114.
913
2.0
139.
214
6.1
158.
8M
,S,σε
100.
08.
310
0.3
82.1
95.1
100.
610
5.6
114.
8U
sing
γ=
12M
,S,σε,r t−
12j
137.
110
.914
3.7
114.
113
0.5
137.
614
4.4
156.
8M
,S,σε
100.
37.
710
0.9
84.2
95.4
100.
610
5.5
114.
4U
sing
γ=
13M
,S,σε,r t−
12j
135.
310
.514
1.2
113.
212
8.9
135.
714
2.2
154.
9M
,S,σε
99.4
7.4
100.
484
.194
.799
.710
4.4
113.
7U
sing
γ=
16M
,S,σε,r t−
12j
128.
110
.113
2.9
106.
812
2.1
128.
613
4.6
146.
6M
,S,σε
94.0
7.3
95.4
79.4
89.1
94.1
99.1
107.
8U
sing
γ=
22M
,S,σε,r t−
12j
113.
410
.511
6.6
91.6
106.
811
3.9
120.
613
2.8
M,
S,σε
79.5
8.8
81.4
61.5
73.8
79.6
85.4
96.1
Gam
ma
7in
vest
or:
EW
I:27
.91.
428
.125
.226
.927
.928
.830
.6V
WI:
33.5
2.6
34.3
28.4
31.8
33.5
35.3
38.5
Usi
ngγ
=7
V,
S,σε
71.0
7.8
74.5
55.2
66.0
71.2
76.3
85.0
M,
V,
S,σε
28.0
39.3
20.3
-65.
914
.337
.052
.371
.2U
sing
γ=
8V
,S,σε
74.6
7.2
78.1
59.7
70.0
74.8
79.5
88.3
M,
V,
S,σε
53.9
23.5
48.4
-5.5
44.7
58.7
69.1
83.4
Tab
le1
Con
tinu
ed
Max
imin
cert
aint
yeq
uiva
lent
:ba
sis
poin
tspe
rm
onth
Por
tfol
ioB
oots
trap
Boo
tstr
apSa
mpl
eB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
/M
ean
Stan
dard
2.5%
ile25
%ile
50%
ile75
%ile
97.5
%ile
Cha
ract
eris
tics
Dev
iati
on
Gam
ma
7in
vest
or,
conti
nu
ed:
Usi
ngγ
=9
M,
S,β
,σε,r t−
12j
112.
019
.012
6.8
70.1
103.
711
4.2
123.
714
0.6
M,
V,
S,σε
67.1
17.2
63.4
28.4
59.8
70.0
77.9
90.3
Usi
ngγ
=10
M,
S,β
,σε,r t−
12j
114.
615
.812
7.0
78.7
106.
411
6.1
124.
914
0.2
M,
S,σε
75.7
13.2
73.7
45.0
69.5
77.6
84.4
95.5
Usi
ngγ
=11
M,
S,σε,r t−
12j
116.
714
.712
3.7
84.3
109.
611
8.3
126.
013
9.5
M,
V,
S,σε
77.6
11.1
75.7
51.9
71.9
78.9
84.9
95.4
Usi
ngγ
=12
M,
S,σε,r t−
12j
116.
813
.512
3.3
85.8
109.
711
8.2
125.
613
8.9
M,
S,σε
81.8
9.4
81.3
60.9
76.6
82.8
88.2
97.9
Usi
ngγ
=13
M,
S,σε,rt−
12j
116.
213
.012
2.1
86.7
109.
311
7.5
124.
713
8.0
M,
S,σε
82.0
8.8
82.0
62.7
76.8
82.6
87.8
97.8
Usi
ngγ
=16
M,
S,σε,r t−
12j
111.
112
.411
5.9
83.5
104.
511
2.3
119.
113
1.8
M,
S,σε
77.9
8.4
78.8
60.6
72.6
78.2
83.7
92.9
Usi
ngγ
=22
M,
S,σε,r t−
12j
97.5
13.0
100.
567
.989
.998
.710
6.4
119.
5M
,S,σε
63.0
10.4
65.0
40.7
56.6
63.6
70.0
81.9
Gam
ma
8in
vest
or:
EW
I:9.
51.
59.
76.
58.
59.
510
.512
.5V
WI:
21.3
2.7
22.3
15.9
19.4
21.3
23.1
26.5
Usi
ngγ
=8
V,
S,σε
60.2
8.5
64.1
42.2
55.1
60.8
66.0
75.4
M,
V,
S,σε
18.7
35.9
9.6
-72.
06.
326
.941
.459
.1
Tab
le1
Con
tinu
ed
Max
imin
cert
aint
yeq
uiva
lent
:ba
sis
poin
tspe
rm
onth
Por
tfol
ioB
oots
trap
Boo
tstr
apSa
mpl
eB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
/M
ean
Stan
dard
2.5%
ile25
%ile
50%
ile75
%ile
97.5
%ile
Cha
ract
eris
tics
Dev
iati
on
Gam
ma
8in
vest
or,
conti
nu
ed:
Usi
ngγ
=9
V,
S,σε
62.8
8.1
66.8
45.4
57.8
63.4
68.4
77.4
M,
V,
S,σε
38.6
25.3
32.1
-18.
829
.243
.754
.069
.0U
sing
γ=
10V
,S,σε
64.4
8.0
68.2
47.5
59.4
64.8
69.8
78.7
M,
S,σε
50.9
18.8
46.6
5.7
43.0
54.4
63.2
75.9
Usi
ngγ
=11
V,
S,σε
65.2
7.9
68.8
48.4
60.3
65.5
70.6
79.5
M,
S,σε
58.3
14.3
55.3
23.9
51.5
60.6
67.8
79.3
Usi
ngγ
=12
M,
S,σε,r t−
12j
94.5
18.0
101.
150
.486
.497
.310
6.1
120.
7M
,S,σε
61.9
12.4
59.9
33.0
56.0
63.6
70.0
80.8
Usi
ngγ
=13
M,
S,σε
76.4
8.7
78.5
57.8
71.3
76.8
82.3
91.6
M,
S,σε
63.2
11.0
62.1
37.8
57.4
64.4
70.5
81.6
Usi
ngγ
=16
M,
S,σε
79.3
7.6
82.0
63.8
74.3
79.5
84.5
93.6
M,
S,σε
60.6
10.1
60.9
38.8
54.6
61.4
67.4
77.8
Usi
ngγ
=22
M,
S,σε
72.8
8.5
75.6
54.8
67.5
73.4
78.8
88.0
M,
S,σε
45.0
12.7
47.2
16.5
37.5
46.1
53.6
66.9
Gam
ma
9in
vest
or:
EW
I:-1
0.2
1.7
-9.9
-13.
5-1
1.3
-10.
2-9
.1-6
.9V
WI:
8.5
2.9
9.7
2.9
6.5
8.5
10.5
14.1
Usi
ngγ
=9
V,
S,σε
48.5
9.8
52.9
26.7
42.8
49.5
55.2
65.1
M,
V,
S,σε
6.3
37.0
-3.7
-78.
2-6
.114
.628
.446
.8
Tab
le1
Con
tinu
ed
Max
imin
cert
aint
yeq
uiva
lent
:ba
sis
poin
tspe
rm
onth
Por
tfol
ioB
oots
trap
Boo
tstr
apSa
mpl
eB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
/M
ean
Stan
dard
2.5%
ile25
%ile
50%
ile75
%ile
97.5
%ile
Cha
ract
eris
tics
Dev
iati
on
Gam
ma
9in
vest
or,
conti
nu
ed:
Usi
ngγ
=10
V,
S,σε
50.6
9.6
54.8
29.4
45.0
51.3
57.1
66.9
M,
S,σε
23.1
26.9
16.0
-42.
613
.028
.940
.555
.9U
sing
γ=
11V
,S,σε
51.7
9.4
55.8
30.8
46.3
52.4
58.2
68.2
M,
S,σε
34.3
19.7
29.0
-14.
925
.838
.247
.260
.6U
sing
γ=
12V
,S,σε
51.9
9.4
56.0
31.1
46.5
52.7
58.3
68.1
M,
S,σε
40.1
16.4
36.5
0.0
33.1
43.0
50.8
63.1
Usi
ngγ
=13
M,
S,σε
56.8
10.9
58.3
32.6
50.9
57.8
64.2
75.0
M,
S,σε
42.9
14.3
40.4
8.0
36.2
45.0
52.3
64.7
Usi
ngγ
=16
M,
S,σε
62.7
9.0
65.1
44.0
57.1
63.3
69.0
79.1
M,
S,σε
41.8
12.5
41.6
13.7
34.9
43.2
50.3
62.0
Usi
ngγ
=22
M,
S,σε
57.6
10.0
60.3
35.8
51.6
58.5
64.5
74.9
M,
S,σε
25.1
16.0
27.7
-12.
016
.026
.936
.051
.6
Gam
ma
10in
vest
or:
EW
I:-3
1.5
2.0
-31.
1-3
5.4
-32.
8-3
1.5
-30.
1-2
7.7
VW
I:-5
.03.
1-3
.6-1
1.2
-7.0
-4.9
-2.8
1.1
Usi
ngγ
=10
V,
S,σε
35.8
11.8
40.7
8.7
29.4
37.1
43.9
54.9
M,
V,
S,σε
-8.6
37.0
-19.
4-1
01.0
-21.
20.
014
.633
.5U
sing
γ=
11V
,S,σε
37.4
11.5
42.0
10.7
31.1
38.5
45.3
56.5
M,
V,
S,σε
7.6
27.2
-0.4
-61.
4-3
.213
.725
.141
.2
Tab
le1
Con
tinu
ed
Max
imin
cert
aint
yeq
uiva
lent
:ba
sis
poin
tspe
rm
onth
Por
tfol
ioB
oots
trap
Boo
tstr
apSa
mpl
eB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
/M
ean
Stan
dard
2.5%
ile25
%ile
50%
ile75
%ile
97.5
%ile
Cha
ract
eris
tics
Dev
iati
on
Gam
ma
10in
vest
orC
onti
nu
ed:
Usi
ngγ
=12
V,
S,σε
37.8
11.5
42.4
11.4
31.5
39.0
45.6
56.5
M,
S,σε
16.1
22.2
10.5
-39.
67.
420
.630
.345
.0U
sing
γ=
13V
,S,σε
37.4
11.7
42.2
10.5
31.1
38.8
45.5
56.2
M,
S,σε
20.7
19.0
16.7
-26.
812
.624
.032
.947
.1U
sin
gγ
=16
M,
S,σε
44.9
10.9
46.9
21.1
38.3
45.8
52.6
64.0
M,
S,σε
21.4
15.9
20.6
-15.
513
.323
.632
.145
.6U
sing
γ=
22M
,S,σε
41.1
12.1
43.8
13.9
34.2
42.4
49.5
61.3
M,
S,σε
3.0
20.5
6.2
-45.
2-7
.95.
817
.035
.2
For
each
of9
inve
stor
s,in
dexe
dby
γi
=2,...,
10w
eev
alua
teth
esa
mpl
ing
dist
ribu
tion
ofth
ece
rtai
nty
equi
vale
ntre
turn
s(a
cros
s10
,000
boot
stra
psa
mpl
es),
for
41di
ffere
ntm
odel
s(o
rse
tsof
char
acte
rist
ics)
andγ∈{γ
i,...,
13,1
6,22}.
The
retu
rns
inal
lca
ses
are
from
the
out-
of-s
ampl
epe
riod
Janu
ary
1975
thro
ugh
Dec
embe
r20
15(4
92m
onth
s).
The
upda
ting
prot
ocol
uses
all
hist
oric
alda
tapr
ior
toth
est
art
ofth
ene
xtou
t-of
-sam
ple
year
,th
ero
lling
prot
ocol
uses
the
prec
edin
g18
0m
onth
spr
ior
toth
est
art
ofth
ene
xtou
t-of
-sam
ple
year
.T
his
tabl
ere
port
sth
epr
oper
ties
ofth
ece
rtai
nty
equi
vale
ntre
turn
from
mod
elth
atpr
oduc
esth
ehi
ghes
t2.
5%ile
,fo
rea
chva
lue
ofγ
,un
der
each
prot
ocol
.
The
upda
ting
resu
lts
are
repo
rted
first
wit
hth
ero
lling
resu
lts
repo
rted
belo
wth
em.
Glo
bal
max
ima
acro
ssal
lγ
valu
esan
dpr
otoc
ols
are
high
light
edin
bold
face
.
The
upda
ting
resu
lts
inth
ista
ble
are
extr
acte
dfr
omT
able
sIA
-1–
IA-9
inth
ein
tern
etap
pend
ix.
Table 2
Means of annual θ coefficients from optimal models
Characteristics used in portfolio selection: M, S, β σε, rt−12j using γ = 3Optimal portfolio for the gamma 2 investor
Bootstrap BootstrapCharacteristic Mean σ Sample 2.5%ile 25%ile 50%ile 25%ile 97.5%ile
M 5.40 0.92 5.54 3.73 4.66 5.49 6.08 7.06S -10.80 1.64 -11.66 -14.11 -12.00 -10.66 -9.49 -8.13β 3.50 2.51 4.63 -1.69 1.68 3.84 5.46 7.52σε -11.89 2.34 -13.53 -16.05 -13.47 -12.11 -10.50 -6.72
rt−12j 9.16 1.48 10.03 6.11 8.26 9.19 10.10 12.10
Characteristics used in portfolio selection: M, S, β σε, rt−12j using γ = 5Optimal portfolio for the gamma 3 investor
Bootstrap BootstrapCharacteristic Mean σ Sample 2.5%ile 25%ile 50%ile 25%ile 97.5%ile
M 3.48 0.58 3.60 2.42 3.01 3.53 3.91 4.53S -7.10 1.08 -7.64 -9.16 -7.93 -7.07 -6.21 -5.30β 1.60 1.55 2.33 -1.49 0.44 1.74 2.84 4.16σε -7.63 1.38 -8.72 -10.17 -8.55 -7.72 -6.81 -4.63
rt−12j 5.66 0.91 6.21 3.78 5.09 5.66 6.23 7.47
Characteristics used in portfolio selection: M, S, β σε, rt−12j using γ = 7Optimal portfolio for the gamma 4 investor
Bootstrap BootstrapCharacteristic Mean σ Sample 2.5%ile 25%ile 50%ile 25%ile 97.5%ile
M 2.55 0.43 2.65 1.79 2.22 2.57 2.86 3.36S -5.44 0.85 -5.83 -6.99 -6.11 -5.47 -4.73 -3.97β 0.73 1.14 1.27 -1.50 -0.13 0.78 1.65 2.64σε -5.63 0.97 -6.45 -7.46 -6.27 -5.67 -5.04 -3.57
rt−12j 4.01 0.68 4.41 2.63 3.59 4.01 4.44 5.35
Characteristics used in portfolio selection: M, S, σε, rt−12j using γ = 9Optimal portfolio for the gamma 5 investor
Bootstrap BootstrapCharacteristic Mean σ Sample 2.5%ile 25%ile 50%ile 25%ile 97.5%ile
M 1.98 0.39 2.02 1.28 1.66 2.01 2.27 2.68S -4.43 0.71 -4.77 -5.67 -5.00 -4.49 -3.86 -3.16σε -4.18 0.80 -4.39 -5.42 -4.85 -4.37 -3.36 -2.89
rt−12j 3.05 0.54 3.35 1.98 2.70 3.05 3.40 4.14
Table 2 Continued
Means of annual θ coefficients from optimal models
Characteristics used in portfolio selection: M, S, σε, rt−12j using γ = 11Optimal portfolio for the gamma 6 investor
Bootstrap BootstrapCharacteristic Mean σ Sample 2.5%ile 25%ile 50%ile 25%ile 97.5%ile
M 1.65 0.32 1.69 1.11 1.39 1.65 1.89 2.29S -3.78 0.63 -4.06 -4.86 -4.28 -3.86 -3.28 -2.61σε -3.76 0.73 -3.94 -4.87 -4.37 -3.94 -2.99 -2.57
rt−12j 2.46 0.47 2.69 1.54 2.15 2.46 2.77 3.40
Characteristics used in portfolio selection: M, S, σε, rt−12j using γ = 13Optimal portfolio for the gamma 7 investor
Bootstrap BootstrapCharacteristic Mean σ Sample 2.5%ile 25%ile 50%ile 25%ile 97.5%ile
M 1.42 0.28 1.45 0.98 1.20 1.39 1.62 2.01S -3.32 0.59 -3.56 -4.30 -3.79 -3.42 -2.85 -2.20σε -3.47 0.69 -3.62 -4.50 -4.05 -3.66 -2.73 -2.34
rt−12j 2.07 0.43 2.25 1.25 1.78 2.06 2.35 2.91
Characteristics used in portfolio selection: M, S, σε using γ = 16Optimal portfolio for the gamma 8, 9, and 10 investors
Bootstrap BootstrapCharacteristic Mean σ Sample 2.5%ile 25%ile 50%ile 25%ile 97.5%ile
M 1.29 0.39 1.35 0.69 0.88 1.37 1.60 1.96S -2.56 0.62 -2.72 -3.49 -3.05 -2.73 -1.98 -1.44σε -3.00 0.69 -3.14 -3.94 -3.58 -3.26 -2.19 -1.91
This table reports the sampling distribution of the time-series means of the θ coefficientson each characteristic from the optimal models for investors with γ values ranging from 2
through 10 in the objective function:T−1∑t=0
(1+rp,t+1)1−γ
1−γ(
1T
),
where: rp,t+1 =Nt∑i=1
(ωi,t + 1
Ntθ′xi,t
)· ri,t+1.
The objective function is optimized at the end of 1974 and every year thereafter through2014 (41 years), using an updating protocol. The characteristic abbreviations are: momentum(M), log size (S), market model β (estimated on the preceding 60 months of returns), theresidual standard deviation from that market model (σε), and the five-year average of nextmonth’s return (rt−12j).
Tab
le3
Fam
a-Fr
ench
-Car
hart
regr
essi
onco
effici
ents
ofbe
nchm
ark
port
folio
s
Reg
ress
ion
Boo
tstr
apB
oots
trap
Sam
ple
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apC
oeffi
cien
tM
ean
σ2.
5%ile
25%
ile50
%ile
75%
ile97
.5%
ileV
alu
e-w
eigh
ted
ind
ex(o
fel
igib
lest
ock
s)
α(b
ps/
mon
th)
2.82
2.41
2.78
-1.9
61.
212.
804.
447.
58M
kt0.
990.
010.
990.
980.
990.
991.
001.
01SM
B-0
.09
0.01
-0.1
0-0
.12
-0.1
0-0
.09
-0.0
9-0
.07
HM
L0.
050.
010.
050.
020.
040.
040.
060.
07M
OM
0.00
0.01
0.00
-0.0
2-0
.01
0.00
0.00
0.01
Equ
ally
-wei
ghte
din
dex
(of
elig
ible
stock
s)
α(b
ps/
mon
th)
8.90
1.23
8.93
6.48
8.08
8.89
9.70
11.3
1M
kt1.
030.
001.
031.
021.
031.
031.
031.
04SM
B0.
480.
010.
480.
470.
480.
480.
480.
49H
ML
0.26
0.01
0.26
0.25
0.26
0.26
0.27
0.27
MO
M-0
.08
0.00
-0.0
8-0
.09
-0.0
8-0
.08
-0.0
8-0
.07
Op
tim
alp
ortf
olio
for
gam
ma
2in
vest
or(u
sin
gγ
=3)
α(b
ps/
mon
th)
296.
4040
.51
325.
9922
3.25
268.
2229
4.32
322.
3938
1.41
Mkt
0.53
0.12
0.57
0.31
0.45
0.53
0.61
0.76
SMB
1.05
0.22
1.19
0.61
0.90
1.05
1.20
1.49
HM
L1.
870.
211.
961.
491.
731.
872.
012.
28M
OM
1.43
0.14
1.38
1.15
1.33
1.43
1.53
1.72
Tab
le3
Con
tinu
edFa
ma-
Fren
ch-C
arha
rtre
gres
sion
coeffi
cien
tsof
benc
hmar
kpo
rtfo
lios
Reg
ress
ion
Boo
tstr
apB
oots
trap
Sam
ple
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apC
oeffi
cien
tM
ean
σ2.
5%ile
25%
ile50
%ile
75%
ile97
.5%
ileO
pti
mal
por
tfol
iofo
rga
mm
a3
inve
stor
(usi
ngγ
=5)
α(b
ps/
mon
th)
192.
5624
.94
211.
2814
6.42
175.
2319
1.39
208.
5824
4.57
Mkt
0.55
0.07
0.57
0.42
0.50
0.55
0.60
0.69
SMB
0.45
0.13
0.52
0.19
0.37
0.45
0.54
0.71
HM
L1.
460.
121.
531.
231.
381.
461.
541.
71M
OM
0.97
0.09
0.95
0.80
0.91
0.97
1.03
1.14
Op
tim
alp
ortf
olio
for
gam
ma
4in
vest
or(u
sin
gγ
=7)
α(b
ps/
mon
th)
143.
6118
.49
157.
2910
9.95
130.
6914
2.93
155.
6818
1.95
Mkt
0.57
0.05
0.58
0.47
0.53
0.56
0.60
0.67
SMB
0.20
0.10
0.25
0.02
0.14
0.20
0.27
0.39
HM
L1.
270.
091.
331.
101.
211.
271.
331.
45M
OM
0.74
0.06
0.73
0.61
0.70
0.74
0.78
0.86
Op
tim
alp
ortf
olio
for
gam
ma
5in
vest
or(u
sin
gγ
=9)
α(b
ps/
mon
th)
115.
4913
.48
123.
0490
.19
106.
2011
4.90
124.
0514
3.39
Mkt
0.57
0.03
0.55
0.50
0.55
0.57
0.59
0.64
SMB
0.05
0.07
0.08
-0.1
00.
000.
050.
100.
20H
ML
1.17
0.07
1.22
1.03
1.11
1.16
1.21
1.31
MO
M0.
630.
050.
640.
540.
600.
630.
660.
72
Tab
le3
Con
tinu
edFa
ma-
Fren
ch-C
arha
rtre
gres
sion
coeffi
cien
tsof
benc
hmar
kpo
rtfo
lios
Reg
ress
ion
Boo
tstr
apB
oots
trap
Sam
ple
Boo
tstr
apB
oots
trap
Boo
tstr
apB
oots
trap
Boo
tstr
apC
oeffi
cien
tM
ean
σ2.
5%ile
25%
ile50
%ile
75%
ile97
.5%
ileO
pti
mal
por
tfol
iofo
rga
mm
a6
inve
stor
(usi
ngγ
=11
)
α(b
ps/
mon
th)
99.3
911
.52
105.
6078
.20
91.3
298
.86
106.
8512
3.38
Mkt
0.60
0.03
0.58
0.54
0.58
0.60
0.62
0.66
SMB
-0.0
40.
06-0
.02
-0.1
7-0
.09
-0.0
40.
000.
08H
ML
1.08
0.06
1.13
0.96
1.04
1.08
1.12
1.20
MO
M0.
530.
040.
540.
450.
500.
530.
560.
61
Op
tim
alp
ortf
olio
for
gam
ma
7in
vest
or(u
sin
gγ
=13
)
α(b
ps/
mon
th)
88.7
010
.20
93.5
469
.85
81.6
388
.25
95.3
610
9.44
Mkt
0.62
0.03
0.60
0.56
0.60
0.62
0.64
0.67
SMB
-0.1
10.
06-0
.10
-0.2
3-0
.15
-0.1
1-0
.07
0.00
HM
L1.
020.
061.
070.
920.
981.
021.
061.
13M
OM
0.46
0.04
0.47
0.39
0.44
0.46
0.49
0.54
Op
tim
alp
ortf
olio
for
gam
ma
8,9,
and
10in
vest
ors
(usi
ngγ
=16
)
α(b
ps/
mon
th)
49.1
15.
7251
.72
38.2
145
.19
48.9
452
.93
60.6
5M
kt0.
600.
020.
590.
560.
590.
600.
620.
65SM
B-0
.15
0.05
-0.1
4-0
.25
-0.1
9-0
.15
-0.1
2-0
.06
HM
L1.
000.
041.
060.
910.
971.
001.
031.
09M
OM
0.41
0.03
0.43
0.35
0.39
0.41
0.43
0.47
The
(out
-of-
sam
ple)
retu
rns
ofth
eop
tim
alpo
rtfo
lios
for
each
inve
stor
inde
xed
byco
effici
ent
ofre
lati
veri
skav
ersi
onar
epr
ojec
ted
linea
rly
onth
efo
urFa
ma,
Fren
ch,
Car
hart
fact
ors
inth
em
onth
sJa
nuar
y19
75th
roug
hD
ecem
ber
2015
(492
mon
ths)
.T
his
tabl
ere
port
sth
esa
mpl
ing
dist
ribu
tion
sof
the
regr
essi
onco
effici
ents
.T
hein
form
atio
nin
this
tabl
eis
extr
acte
dfr
omT
able
sIA
-17
thro
ugh
IA-3
0of
the
Inte
rnet
App
endi
x.
Table 4
Portfolio moments of benchmark portfolios formed using eligible stocks
Return BootstrapProperty Mean σ 2.5%ile 25%ile 50%ile 75%ile 97.5%ile
VWIMean 1.08 0.02 1.03 1.06 1.08 1.09 1.12
Std Dev 4.38 0.03 4.33 4.36 4.38 4.40 4.43Median 1.35 0.06 1.23 1.31 1.35 1.39 1.47
Intq Rng 5.40 0.10 5.20 5.33 5.40 5.46 5.59Minimum -22.28 0.51 -23.27 -22.62 -22.29 -21.93 -21.25Skewness 0.32 0.02 0.27 0.31 0.32 0.34 0.37Kurtosis 0.30 0.09 0.13 0.24 0.30 0.36 0.48
SR (ann.) 0.54 0.02 0.50 0.53 0.54 0.55 0.57
EWIMean 1.33 0.01 1.31 1.32 1.33 1.34 1.35
Std Dev 5.13 0.01 5.10 5.12 5.13 5.13 5.15Median 1.59 0.05 1.48 1.55 1.59 1.63 1.69
Intq Rng 6.18 0.08 6.03 6.13 6.18 6.23 6.33Minimum -25.93 0.30 -26.51 -26.13 -25.93 -25.72 -25.35Skewness 0.33 0.01 0.30 0.32 0.33 0.33 0.35Kurtosis 0.31 0.06 0.20 0.27 0.31 0.35 0.42
SR (ann.) 0.63 0.01 0.62 0.63 0.63 0.64 0.65
M, S, β, σε, rt−12j Optimal for gamma 2 investorMean 5.49 0.46 4.65 5.17 5.46 5.79 6.45
Std Dev 14.19 0.98 12.41 13.51 14.13 14.83 16.25Median 5.66 0.53 4.68 5.30 5.65 6.01 6.76
Intq Rng 16.48 1.27 14.16 15.57 16.41 17.30 19.17Minimum -53.15 6.37 -67.83 -56.77 -52.41 -48.73 -42.86Skewness 0.44 0.07 0.31 0.39 0.44 0.49 0.57Kurtosis 0.51 0.19 0.15 0.38 0.51 0.64 0.90
SR (ann.) 1.24 0.06 1.14 1.21 1.24 1.28 1.35
M, S, β, σε, rt−12j Optimal for gamma 3 investorMean 3.88 0.28 3.37 3.69 3.87 4.06 4.47
Std Dev 9.42 0.58 8.35 9.02 9.39 9.79 10.64Median 4.09 0.33 3.48 3.86 4.08 4.30 4.75
Intq Rng 10.62 0.78 9.14 10.08 10.58 11.12 12.24Minimum -36.14 4.50 -46.83 -38.50 -35.51 -33.07 -29.22Skewness 0.51 0.07 0.37 0.46 0.51 0.55 0.64Kurtosis 0.62 0.20 0.24 0.47 0.61 0.75 1.04
SR (ann.) 1.28 0.05 1.18 1.25 1.28 1.32 1.39
Table 4 Continued
Portfolio moments of benchmark portfolios formed using eligible stocks
Return BootstrapProperty Mean σ 2.5%ile 25%ile 50%ile 75%ile 97.5%ile
M, S, β, σε, rt−12j Optimal for gamma 4 investorMean 3.13 0.21 2.75 2.99 3.12 3.27 3.56
Std Dev 7.33 0.42 6.57 7.04 7.32 7.61 8.19Median 3.34 0.24 2.89 3.17 3.33 3.50 3.83
Intq Rng 8.03 0.57 7.00 7.63 8.01 8.40 9.19Minimum -29.52 4.38 -40.29 -31.76 -28.79 -26.43 -23.17Skewness 0.57 0.07 0.44 0.53 0.57 0.62 0.71Kurtosis 0.73 0.21 0.34 0.59 0.73 0.87 1.17
SR (ann.) 1.30 0.05 1.19 1.26 1.29 1.33 1.40
M, S, σε, rt−12j Optimal for gamma 5 investorMean 2.71 0.15 2.43 2.61 2.70 2.80 3.01
Std Dev 6.26 0.29 5.72 6.06 6.25 6.45 6.87Median 2.94 0.18 2.60 2.82 2.94 3.07 3.32
Intq Rng 6.63 0.39 5.90 6.36 6.62 6.90 7.44Minimum -27.96 4.69 -38.74 -30.82 -27.27 -24.48 -20.79Skewness 0.66 0.06 0.54 0.62 0.66 0.70 0.78Kurtosis 0.84 0.21 0.46 0.70 0.83 0.97 1.26
SR (ann.) 1.28 0.05 1.19 1.25 1.28 1.32 1.38
M, S, σε, rt−12j Optimal for gamma 6 investorMean 2.45 0.13 2.22 2.36 2.44 2.53 2.72
Std Dev 5.62 0.24 5.17 5.45 5.61 5.77 6.11Median 2.67 0.16 2.36 2.56 2.67 2.77 2.99
Intq Rng 5.86 0.33 5.24 5.64 5.85 6.08 6.53Minimum -26.87 4.53 -36.72 -29.75 -26.45 -23.50 -19.48Skewness 0.67 0.06 0.55 0.63 0.67 0.71 0.79Kurtosis 0.87 0.20 0.50 0.73 0.86 1.00 1.28
SR (ann.) 1.27 0.05 1.18 1.24 1.27 1.31 1.37
M, S, σε, rt−12j Optimal for gamma 7 investorMean 2.28 0.11 2.07 2.20 2.27 2.35 2.50
Std Dev 5.22 0.20 4.85 5.08 5.21 5.35 5.64Median 2.47 0.14 2.21 2.37 2.47 2.57 2.77
Intq Rng 5.38 0.28 4.87 5.18 5.37 5.56 5.96Minimum -26.69 4.39 -36.05 -29.50 -26.38 -23.48 -19.16Skewness 0.68 0.06 0.56 0.64 0.68 0.72 0.80Kurtosis 0.88 0.19 0.52 0.75 0.87 1.01 1.27
SR (ann.) 1.25 0.05 1.16 1.22 1.25 1.29 1.35
Table 4 Continued
Portfolio moments of benchmark portfolios formed using eligible stocks
Return BootstrapProperty Mean σ 2.5%ile 25%ile 50%ile 75%ile 97.5%ile
M, S, σε Optimal for gamma 8, 9, and 10 investorsMean 1.82 0.07 1.69 1.77 1.82 1.87 1.96
Std Dev 4.64 0.12 4.41 4.56 4.63 4.72 4.87Median 1.96 0.10 1.76 1.89 1.96 2.03 2.17
Intq Rng 4.73 0.19 4.37 4.60 4.72 4.85 5.11Minimum -22.24 2.30 -27.33 -23.65 -21.99 -20.59 -18.45Skewness 0.67 0.05 0.57 0.63 0.67 0.71 0.77Kurtosis 1.07 0.19 0.72 0.94 1.07 1.20 1.46
SR (ann.) 1.07 0.04 0.99 1.04 1.07 1.10 1.15
This table provides sampling distributions (formed from 10,000 bootstrapsamples) of the (out-of-sample) return distribution moments of the optimalportfolios for investors indexed by their coefficient of relative risk aversion(gamma). There are 492 monthly returns, over the period January 1975through December 2015.
Intq Rng refers to the interquartile range (the difference between the 75%ilereturn and the 25%ile return).
Skewness is the estimate (K3) of the third moment:
K3 =r+.95 − r
−.05
r+.5 − r−.5
− 2.63
Kurtosis is the estimate (K4) of the fourth moment:
K4 =r.95 − r.05
r.75 − r.25− 2.90
Where:r+.95 is the mean of the highest 5% of returns,r−.05 is the mean of the smallest 5% of returns,r+.5 is the mean of the top half of returns,and r−.5 is the mean of the bottom half of returns;and rx is the observation corresponding to the x%ile of the return data.
SR (ann.) is the monthly Sharpe ratio ×√
12.
Tab
le5
Mon
th-b
y-M
onth
Fac
tor
Exp
osu
reP
anel
A.
Mon
th-b
y-m
onth
FF
Cfa
ctor
retu
rns
Fact
orA
llJa
nFe
bM
arA
prM
ayJu
nJu
lA
ugSe
pO
ctN
ovD
ecm
onth
sRm−r f
0.67∗∗
1.21
0.47
0.93
1.37∗
0.89
0.39
0.10
0.08
-0.8
40.
311.
68∗
1.46∗
(0.
20)
(0.
81)
(0.
64)
(0.
60)
(0.
56)
(0.
57)
(0.
53)
(0.
65)
(0.
80)
(0.
71)
(1.
03)
(0.
68)
(0.
51)
SMB
0.26
1.41∗
0.98
0.35
-0.1
80.
381.
03-0
.66
-0.1
30.
06−
1.28∗
0.45
0.75∗
(0.
14)
(0.
48)
(0.
63)
(0.
55)
(0.
46)
(0.
41)
(0.
44)
(0.
44)
(0.
42)
(0.
36)
(0.
53)
(0.
43)
(0.
35)
HM
L0.
30∗
0.92
0.58
1.05∗∗
0.70
0.00
-0.1
90.
640.
580.
16-0
.54
-0.5
50.
26(
0.13
)(
0.60
)(
0.65
)(
0.35
)(
0.42
)(
0.31
)(
0.41
)(
0.47
)(
0.39
)(
0.38
)(
0.44
)(
0.50
)(
0.43
)M
OM
0.65∗∗
-1.2
81.
620.
60-1
.23
-0.1
32.
081.
27-0
.36
2.02
0.45
0.79
1.91
(0.
20)
(0.
90)
(0.
65)
(0.
54)
(1.
01)
(0.
60)
(0.
60)
(0.
48)
(0.
46)
(0.
52)
(0.
64)
(0.
73)
(0.
62)
Pan
elB
.T
imin
gbi
ases
inFa
ma
Fren
chC
arha
rtre
gres
sion
alph
asin
the
opti
mal
port
folio
ofth
ega
mm
a2
inve
stor
form
edus
ingγ
=3
wit
hch
arac
teri
stic
s:M
,S,β
,σε,r t−
12j
Bia
sdu
eto
:M
arke
tSM
BH
ML
MO
MT
otal
Bia
sα
Tot
alB
ias:
Mea
n5.
3031
.04
9.50
0.41
46.2
529
6.40
Std
Dev
5.24
8.18
5.26
11.0
117
.07
40.5
12.
5%ile
-4.8
716
.06
-0.7
3-2
1.45
13.8
022
3.25
Med
ian
5.23
30.7
59.
440.
4145
.89
294.
3297
.5%
ile15
.72
47.9
920
.19
22.0
880
.46
381.
41
Vol
atilit
yT
imin
gB
ias:
Mea
n16
.36
22.6
013
.74
-15.
6037
.10
Std
Dev
4.56
8.08
5.47
8.77
15.6
42.
5%ile
7.67
7.62
3.21
-32.
907.
83M
edia
n16
.30
22.2
913
.65
-15.
5936
.62
97.5
%ile
25.6
339
.43
24.8
61.
5968
.77
Mea
nT
imin
gB
ias:
Mea
n-1
1.06
8.43
-4.2
416
.01
9.15
Std
Dev
2.80
1.95
2.11
3.94
5.89
2.5%
ile-1
6.79
4.72
-8.5
68.
29-2
.47
Med
ian
-10.
978.
38-4
.14
16.0
19.
1897
.5%
ile-5
.81
12.3
9-0
.30
23.7
620
.56
Table 5 Month-by-Month Factor Exposure Continued
Panel C. Timing biases in Fama French Carhart regression alphas in the optimal portfolio of thegamma 3 investor formed using γ = 5 with characteristics: M, S, β, σε, rt−12j
Bias due to:Market SMB HML MOM Total Bias α
Total Bias: Mean 1.52 16.16 3.47 -1.18 19.97 192.56Std Dev 3.27 5.12 3.33 6.90 10.64 24.942.5%ile -4.86 6.70 -2.95 -14.86 0.07 146.42Median 1.53 16.03 3.42 -1.20 19.63 191.39
97.5%ile 7.96 26.67 10.27 12.47 41.50 244.57
Volatility Timing Bias: Mean 9.47 10.32 6.39 -10.91 15.27Std Dev 2.82 5.07 3.39 5.47 9.642.5%ile 4.03 0.89 -0.01 -21.64 -2.82Median 9.41 10.17 6.33 -10.98 14.94
97.5%ile 15.14 20.69 13.33 -0.18 34.78
Mean Timing Bias: Mean -7.95 5.84 -2.92 9.73 4.70Std Dev 1.73 1.23 1.31 2.48 3.762.5%ile -11.47 3.50 -5.60 4.85 -2.82Median -7.90 5.80 -2.89 9.73 4.69
97.5%ile -4.64 8.31 -0.51 14.65 11.97
Panel D. Timing biases in Fama French Carhart regression alphas in the optimal portfolio of thegamma 4 investor formed using γ = 7 with characteristics: M, S, β, σε, rt−12j
Bias due to:Market SMB HML MOM Total Bias α
Total Bias: Mean -0.26 9.20 0.67 -2.21 7.42 143.61Std Dev 2.49 3.78 2.49 5.16 8.01 18.492.5%ile -5.02 2.20 -4.11 -12.50 -7.71 109.95Median -0.27 9.09 0.69 -2.15 7.24 142.93
97.5%ile 4.63 16.94 5.63 7.82 23.93 181.95
Volatility Timing Bias: Mean 6.31 4.54 3.01 -8.99 4.87Std Dev 2.13 3.73 2.53 4.10 7.242.5%ile 2.31 -2.38 -1.83 -17.17 -8.76Median 6.25 4.43 2.98 -8.98 4.69
97.5%ile 10.59 12.15 8.12 -0.99 19.93
Mean Timing Bias: Mean -6.57 4.66 -2.34 6.78 2.54Std Dev 1.32 0.93 0.99 1.84 2.842.5%ile -9.23 2.89 -4.32 3.12 -2.98Median -6.52 4.65 -2.31 6.78 2.55
97.5%ile -4.09 6.53 -0.45 10.34 8.08
Table 5 Month-by-Month Factor Exposure Continued
Panel E. Timing biases in Fama French Carhart regression alphas in the optimal portfolio of thegamma 5 investor formed using γ = 9 with characteristics: M, S, σε, rt−12j
Bias due to:Market SMB HML MOM Total Bias α
Total Bias: Mean -1.04 5.32 -1.74 -4.50 -1.97 115.49Std Dev 1.92 2.87 1.87 3.67 5.72 13.482.5%ile -4.81 -0.13 -5.37 -11.84 -12.85 90.19Median -1.04 5.24 -1.75 -4.50 -2.04 114.90
97.5%ile 2.77 11.17 1.99 2.74 9.47 143.39
Volatility Timing Bias: Mean 5.20 1.42 0.78 -9.21 -1.82Std Dev 1.55 2.83 1.88 2.95 5.032.5%ile 2.20 -3.97 -2.82 -15.07 -11.38Median 5.19 1.34 0.75 -9.21 -1.97
97.5%ile 8.33 7.06 4.61 -3.46 8.34
Mean Timing Bias: Mean -6.24 3.90 -2.53 4.71 -0.15Std Dev 0.97 0.73 0.74 1.33 2.042.5%ile -8.23 2.52 -4.00 2.15 -4.10Median -6.24 3.90 -2.51 4.69 -0.17
97.5%ile -4.36 5.35 -1.13 7.37 3.88
Panel F. Timing biases in Fama French Carhart regression alphas in the optimal portfolio of thegamma 6 investor formed using γ = 11 with characteristics: M, S, σε, rt−12j
Bias due to:Market SMB HML MOM Total Bias α
Total Bias: Mean -1.55 3.15 -2.30 -4.27 -4.97 99.39Std Dev 1.69 2.48 1.59 3.18 4.97 11.522.5%ile -4.90 -1.55 -5.41 -10.54 -14.23 78.20Median -1.57 3.10 -2.32 -4.29 -5.13 98.86
97.5%ile 1.77 8.13 0.87 2.00 5.23 123.38
Volatility Timing Bias: Mean 4.12 -0.26 -0.09 -7.93 -4.16Std Dev 1.36 2.44 1.60 2.58 4.372.5%ile 1.47 -4.95 -3.13 -12.96 -12.19Median 4.11 -0.30 -0.12 -7.94 -4.31
97.5%ile 6.81 4.63 3.13 -2.90 4.89
Mean Timing Bias: Mean -5.67 3.41 -2.21 3.66 -0.80Std Dev 0.85 0.63 0.64 1.14 1.762.5%ile -7.37 2.21 -3.50 1.44 -4.22Median -5.65 3.40 -2.21 3.66 -0.83
97.5%ile -4.05 4.67 -0.99 5.92 2.67
Table 5 Month-by-Month Factor Exposure Continued
Panel G. Timing biases in Fama French Carhart regression alphas in the optimal portfolio of thegamma 7 investor formed using γ = 13 with characteristics: M, S, σε, rt−12j
Bias due to:Market SMB HML MOM Total Bias α
Total Bias: Mean -1.95 1.59 -2.69 -4.29 -7.34 88.70Std Dev 1.55 2.23 1.44 2.86 4.50 10.202.5%ile -5.08 -2.72 -5.47 -9.85 -15.95 69.85Median -1.96 1.55 -2.72 -4.28 -7.40 88.25
97.5%ile 1.05 6.03 0.20 1.28 1.79 109.44
Volatility Timing Bias: Mean 3.35 -1.51 -0.68 -7.20 -6.04Std Dev 1.23 2.20 1.45 2.32 3.972.5%ile 0.97 -5.76 -3.49 -11.79 -13.48Median 3.34 -1.54 -0.71 -7.18 -6.13
97.5%ile 5.77 2.87 2.23 -2.67 1.94
Mean Timing Bias: Mean -5.30 3.09 -2.01 2.91 -1.30Std Dev 0.77 0.57 0.58 1.02 1.602.5%ile -6.82 2.01 -3.18 0.93 -4.38Median -5.30 3.08 -2.00 2.91 -1.32
97.5%ile -3.82 4.22 -0.91 4.94 1.91
Panel H. Timing biases in Fama French Carhart regression alphas in the optimal portfolio of thegamma 8, 9, and 10 investors formed using γ = 16 with characteristics: M, S, σε
Bias due to:Market SMB HML MOM Total Bias α
Total Bias: Mean -3.44 -5.59 -5.13 -4.52 -18.68 49.11Std Dev 1.10 1.68 1.15 2.19 3.01 5.722.5%ile -5.56 -8.86 -7.38 -8.83 -24.53 38.21Median -3.45 -5.63 -5.13 -4.51 -18.70 48.94
97.5%ile -1.30 -2.22 -2.87 -0.24 -12.85 60.65
Volatility Timing Bias: Mean 0.41 -7.15 -4.21 -4.25 -15.20Std Dev 0.89 1.66 1.15 1.81 2.732.5%ile -1.32 -10.36 -6.42 -7.82 -20.54Median 0.40 -7.17 -4.21 -4.23 -15.22
97.5%ile 2.17 -3.87 -1.98 -0.73 -9.95
Mean Timing Bias: Mean -3.85 1.56 -0.92 -0.27 -3.48Std Dev 0.56 0.40 0.42 0.74 1.242.5%ile -4.94 0.76 -1.75 -1.73 -5.89Median -3.85 1.56 -0.93 -0.27 -3.48
97.5%ile -2.73 2.35 -0.10 1.18 -0.96
Table 5 ContinuedMonth-by-month factor exposure
The numbers in parentheses below the mean returns in Panel A are standard errors.
Total bias is defined:
112
12∑m=1
bm,jf j,m − buj · f
uj
where:buj is the unconditional loading of the portfolio returns on factor j.fj,m is the return on factor j in month m.bm,j is the loading of the portfolio return in month m on fj,m.
bj =112
12∑m=1
bm,j
Volatility bias is defined:
fuj (bj − buj )
where:fuj is the unconditional mean of the return on factor j.
Risk-premium (or mean-) timing bias is defined as the difference between total bias and volatility-timing bias.