Bilateral trade ties, elections and foreign aid allocation: A comparison across...
Transcript of Bilateral trade ties, elections and foreign aid allocation: A comparison across...
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Bilateral trade ties, elections and foreign aid allocation:
A comparison across donors
Nabeela Alam!
Brandeis University International Business School
Job Market Paper
August 2012
Abstract: This paper informs the aid effectiveness debate by examining non-development motives of bilateral foreign aid flows. Using a panel of five bilateral donors and a hundred recipient countries from
1975-2008, I find that trade ties, recipients' access to donor markets, elections and political
competitiveness in the recipient country are associated with changes in foreign aid commitments. I show
that the US gives more aid to its non-competitive, larger trade partners, but cuts their aid ahead of elections. It substitutes aid with market access for non-competitive countries for which it is an important
export market, but not during election years. Germany, Japan and UK give more aid to countries with
competitive electoral systems, but for these countries Japan and UK substitute aid with trade. The substitution disappears for UK during election years. Japan and UK also reward countries for which they
are important export markets with more aid, but only during non-election years for Japan. During
election years, Germany cuts aid to non-competitive countries, but gives more aid to non-competitive countries for which it is an export destination. There is some evidence that France substitutes aid with
market access for politically competitive countries.
! Email: [email protected]
I would like to thank my advisors, Cathy Mann and Can Erbil, for their support and guidance, and Kathryn Graddy, Nidhya Menon and other seminar participants at Brandeis University and the for their insightful comments and
suggestions. I am also grateful to seminar participants at Babson College and Whitman College for their comments
and suggestions on an earlier version of the paper.
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1 Introduction
Despite the large amounts of aid spent on developing countries, studies give conflicting
results for the impact of aid on growth (Boone 1994; Burnside and Dollar 2000, 2004; Easterly
2003, Easterly, Levine, and Roodman 2003; Rajan and Subramanian 2008). Even when aid has
a positive impact on growth, the effects are modest (Clemens, Radelet, and Bhavnani 2004;
Clemens et al. 2011). However, this is not surprising given that donor interests can drive aid
allocation (Alesina and Dollar 2000; Boone 1996), and that actual patterns of aid allocation
differ from poverty-efficient aid allocation patterns (Collier and Dollar 2002).
While aid based on donor interests can still be consistent with developmental objectives
when there are mutual benefits, this need not be always true. In this light it is important to
identify all the determinants of aid, both developmental and non-developmental. Studies should
take into account extra-development motives when evaluating the impact of aid. Indeed they
should also evaluate whether observed allocation strategies are consistent with the
developmental objectives of foreign assistance. Thus identifying the determinants of foreign aid
will help make the foreign aid allocation process more transparent and accountable.
In this paper, I contribute to an understanding of foreign aid determinants by examining
the relationship between bilateral trade and foreign aid flows for five major donors, namely
France, Germany, Japan, the United Kingdom and the United States. I further test whether
donors differentially adjust foreign aid flows ahead of elections in recipient countries on the
basis of their bilateral trade relationships, and whether donors distinguish between countries with
politically competitive and non-competitive electoral systems.
I add to the literature on aid allocation in three novel ways: First, I ask whether it is the
donor’s trade interest or the recipient’s trade interests that influences foreign aid flows. I define
donor trade interest as the share of donor's total trade with a recipient. Recipient trade interest is
the share of a recipient's total exports flowing to a donor, and therefore measures the recipient's
access to a donor market. Previous literature comparing aid allocation across donors has focused
on donor trade interests (Berthélemy 2006; Berthélemy and Tichit 2004).
Next, I test the aid-trade relationships using bilateral trade ties over different time
horizons to reflect potential short-term and long-term aid allocation strategies. To this end I look
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at a regime-specific measure of trade ties as well as the more conventional year-to-year measure.
The former is the year-to-date cumulative trade ties calculated from the start of a recipient
government’s tenure. The two measures help distinguish whether donor governments are
sensitive to year-to-year differences in trade relationships, or whether it is the cumulative trade
relationship over a recipient regime’s tenure that matters.
Finally, I test for election year effects on foreign aid flows, and if there are differential
effects during elections for recipients with closer trade ties. I also examine if aid allocation
behaviour depends on whether the electoral process in the recipient country is politically
competitive or not.
I find that both donor trade interests and recipient trade interests matter for donors' aid
allocation decisions, but in different ways for each donor. The United States gives more aid to
non-competitive countries with which it has larger trade ties, but cuts aid ahead of elections for
them. It also treats aid and market access as substitutes for non-competitive countries during
non-election years. Germany cuts aid ahead of elections for non-competitive countries with
which it trades more. Germany, Japan and the UK all pledge more aid to countries if they are
politically competitive, but Japan and the UK treat trade and aid as substitutes for these
politically competitive countries. However, the UK mutes this substitution behaviour during
election years so that politically competitive countries that trade more with the UK don't face a
decrease in aid during election years. Both Japan and the UK also give more aid to politically
competitive countries that export more to them. During election years however, Japan decreases
its aid commitments to these countries. France is the only country for which there are no
election year effects and donor trade interests. The latter result is in contrast to previous findings
that France is less altruistic in giving aid (Berthélemy 2006; Rajan and Subramanian 2008).
There is some evidence however that for politically competitive countries, France treats market
access and aid as substitutes.
The objective of this paper is to establish some empirical facts about aid allocation
strategies by different donors. Assessing how foreign aid commitments change with trade
relationships, election events and political competitiveness in recipient countries helps us better
understand the foreign aid process. The overarching goal is to contribute to the aid effectiveness
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literature, which can use these empirical facts to further investigate the motivations behind
foreign aid flows and evaluate the effectiveness of aid based on these objectives.
This paper also contributes to the literature on aid allocation behaviour motivated by
donor interests. Past studies find that donors give aid based on their own geopolitical and
strategic interests (Alesina and Dollar 2000; Boone 1996; Dreher, Nunnenkamp, and Thiele
2008; Faye and Niehaus 2010; Harrigan and Wang 2011; Kuziemko and Werker 2006), or their
economic and commercial interests (Berthélemy 2006; Berthélemy and Tichit 2004; Osei,
Morrissey, and Lloyd 2004). To the best of my knowledge only one other study by Faye and
Niehaus (2010) looks at election year effects of foreign aid flows,1 but they look at differential
effect of elections by political alignment measured by voting coincidence in the United Nations
General Assembly. Moreover, they look at the pooled behaviour of bilateral aid donors and so
constrain all donors in their sample to have on average the same aid allocation strategy. I test the
aid allocation strategies of each donor separately to be able to capture differences in donor
behaviour.
The remainder of the paper is structured as follows. Section 2 discusses the data, and
Section 3 presents the empirical strategy. Section 4 presents and analyzes the results, with
robustness checks discussed in Section 5. Finally, Section 6 concludes. All tables and figures
are in Appendices A and B at the end.
2 Data
I study aid allocation using a dataset composed of five bilateral aid donors and 100
recipient countries from 1975 to 2008, with a total of 12,335 observations. Table 1 lists the
recipient countries. Each observation is a donor-recipient-year triple with information on
bilateral trade and aid, political variables and demographic controls as described below.
The source for aid data is the International Development Statistics (2009) database
compiled by the Development Cooperation Directorate (DCD) and Development Assistance
Committee (DAC) of the Organisation for Economic Cooperation and Development (OECD). I
use annual Official Development Assistance (ODA) figures disaggregated at the donor-recipient
1 A related study by Dreher and Jensen (2007) finds that closer allies (measured by UNGA voting alignment) of the
Group of 7 (G7) countries were given fewer IMF conditions ahead of elections in the recipient countries.
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level, and converted to constant 2000 US dollars. Three conditions must be met in order for
foreign aid to qualify as ODA by the OECD's DAC: (i) the aid transfer must originate from the
official (government) sector;2 (ii) the primary goal of the aid should be to promote economic
development and welfare of the recipient country; and (iii) any loans must be made on
concessional terms and carry a grant element of at least 25 per cent.3 ODA includes flows to
recipient country governments and its institutions, non-governmental organisations, civil society
organisations and multilateral development organisations recognized by the DAC. It does not
constitute military aid, or any flows to or from private individuals.
Figure 1 shows the breakdown between bilateral and multilateral aid commitments.
Overall ODA commitments doubled from 60 billion dollars in 1975 to about 123 billion dollars
in 2007.4 Bilateral aid accounts for roughly 75 per cent of total aid commitments during this
period. I use data for total bilateral commitments, consisting of loans and grants, rather than
bilateral disbursements. Commitments are the more appropriate measure to address the
questions in this paper for several reasons. First, aid disbursements are more likely to reflect
both a donor’s willingness to make a foreign aid transfer, and the recipient government’s
decision to implement or ignore selected donor-approved projects. The response of aid
disbursements to changes in bilateral trade ties would capture both donor response and recipient
response, and makes inference on donor aid allocation behaviour less convincing. Other studies
(Berthélemy 2006; Berthélemy and Tichit 2004; Osei, Morrissey, and Lloyd 2004) also use aid
commitments as it more accurately reflects the donor’s aid allocation decision than do aid
disbursements. The second reason for using commitments has to do with the timing of elections
in recipient countries. To test whether donors adjust aid flows ahead of elections, the variable
for the aid allocation decision must be determined before the elections. While both the lag of aid
disbursements and contemporaneous aid commitments satisfy this property, the problem of
disbursements reflecting both donor and recipient decisions is arguably more acute ahead of
elections.5 In addition, commitments for a given year are announced at the beginning of that
year, with the budget process already underway the previous year. Thus commitments for a
2 Official aid organisations include, for instance, the USAID for the United States, the DFID for the United
Kingdom, and SIDA for Sweden. 3 See OECD (2010) for detailed definitions. 4 ODA amounts in Figures 1 and 2 are in constant 2007 US dollars. 5 See Alam (2012) for a model of how donor-recipient government interactions determine aid disbursements ahead
of elections.
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given year will more accurately reflect election year concerns of the donor country, even for
elections held in the first quarter of the year.6
Figure 2 shows the composition of the OECD DAC’s bilateral aid commitments by a
selected group of donor countries from 1975 to 2008. Ten out of twenty-three7 members account
for approximately 80 per cent of total bilateral commitments each year. The United States is the
largest contributor by aid volume, and accounts for about 25 per cent of total DAC
commitments. The other leading donors are France and Germany (together contributing about
25 per cent), Japan (10 to 20 percent) and the United Kingdom (5 per cent). The Netherlands and
four Scandinavian countries – Denmark, Finland, Norway and Sweden – together contribute
another 10 to 15 percent of total DAC ODA commitments. Based on these numbers I focus on
the aid allocation behaviour of the five largest donors that are most likely to have political and
strategic considerations: France, Germany, Japan, the United Kingdom, and the United States.8
The primary source for bilateral trade data is the International Monetary Fund’s Direction
of Trade Statistics (DOTS) (2010) for the period 1975 to 2008. The database separately reports
both exports and imports between any two countries. I construct two different measures of
bilateral trade ties. The first is the trade intensity of a donor-recipient pair relative to the donor’s
total trade volume, and reflects the importance of the recipient as a trading partner for the donor.
This measures the importance of trade ties from the donor’s perspective, and I use it to test
whether trade links with the recipient drives donor aid allocation. The second measure gauges
the importance of trade ties from the recipient perspective, and is given by the recipient’s exports
to the donor as a share of the recipient country’s total exports. This is in effect an indicator of
the importance of the donor as an export destination for the recipient. I use this measure to test
whether donors view foreign aid as a substitute for giving market access to recipient countries
exports. Table 2 summarizes the variables used in the study and their sources, and Table 3
reports the summary statistics for ODA and trade and export shares by donor.
6 Between 13 and 15 per cent of the election events in the sample occurs in January and February for each donor,
and only about 4.5 per cent occur in January. 7 Number of DAC members increased to twenty-four in January 2010 with the inclusion of South Korea. 8 China has also become a major aid donor, as estimated by several studies (McCormick 2008; Walz and
Ramachandran 2010; Woods 2008), and higher estimates put Chinese bilateral aid amounts close to US bilateral aid
(Lum 2009). However, China and some other new emerging market aid donors such as India do not report their aid
figures to the OECD's DAC.
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Election and political competitiveness variables for the recipient countries are from the
World Bank Database of Political Institutions (DPI) by Beck et al. (2001) and updated by Keefer
(2009). The DPI 2009 version has data available from 1975 to 2008, and this limits the time
period of my analysis. The database reports figures for both executive and legislative elections,
but I use only executive elections as donor-recipient negotiations on aid and other strategic
considerations are more likely to depend on the identity of the head of state rather than the
recipient’s constituent domestic legislature. The measure of political competitiveness, on the
other hand, encompasses competition in both the executive and legislative branches. I expect
that the donors’ perception of the degree of democracy in a recipient country will be determined
by the overall political process, and not only the part of the process that elects the chief
executive.
Other demographic controls such as GDP, population, and infant mortality are from the
World Bank’s World Development Indicators (2009) and are listed in Table 2.
3 Empirical Strategy
This paper uses a simple regression framework to study the effect of donor-recipient
trade ties on ODA flows. The regression specification includes both measures of trade ties: the
donor’s trade interests and the recipient’s trade interests. Equation (1) outlines the baseline
model for estimating the effect of the donor-recipient bilateral trade relationship on ODA flows:
!
ODAdrt = "1Tradedrt#1 + "
2Exportdrt#1 + $ X drt#1b + µrt + %drt . (1)
The variables of interest Tradedrt-1 and Exportdrt-1 are one year lagged time varying measures
that capture donor trade interests and recipient trade interests respectively for each donor (d) and
recipient (r) pair. The coefficient
!
"1 gives the effect of the donor trade interests on foreign aid
flows and
!
"2 gives the effect of the recipient trade interests.
The first measure of bilateral trade ties denoting donor trade interests, Trade, is the
volume of bilateral trade between a donor-recipient pair as a share of the donor’s total trade
volume in a given year. It captures the importance of the recipient as a trading partner to the
donor, and is calculated as:
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!
Tradedrt =Exportdrt + Importdrt
Total Exportdt + Total Importdt,
where Exportdrt is the volume of recipient exports to the donor and Importdrt is the volume of
recipient imports flowing from the donor in year t . Total Exportdt is the donor's total export
volume to all countries and Total Importdt is its total imports during the same time period. Thus
using the above measure, equation (1) tests whether the donor’s share of trade with a recipient in
year t–1 affects ODA flowing from the donor to the recipient in year t. This may have a positive
or negative effect on aid flows as explained below and the final sign on the coefficient
!
"1 will be
an empirical balance.
Donor trade interests can influence foreign aid flows in a number of ways. The donor
may wish to financially support a country that is economically important because it is an
important export market. Tied aid falls into this category, but the causality would go from aid to
trade in this case, with the donor requiring a specified portion of the aid be used in purchases
from the donor itself.9 Alternately, the donor may want to provide financial assistance to a
country from which it imports heavily, especially if the imports are strategically important. The
donor may, on the other hand, simply wish to reward aid recipient countries with which it has
better relations through larger trade ties. Each scenario above is framed in terms of the donor’s
trade interests, and stronger trade ties with a recipient should elicit larger aid flows to the
recipient with
!
"1 being positive.
On the other hand, larger volumes of exports to a recipient may signal an increasing
ability of the recipient country to purchase goods and services, and the donor may decide to
reduce aid. This case is the antithesis of tied aid, and the coefficient on Trade ties will be
negative. We should also expect to see a negative relationship between trade and aid if the donor
sees the two as substitutes, giving less aid to countries with which it trades more. While this
measure captures the donor’s trade interests, it does not distinguish between whether a recipient
is important to the donor via its exports or its imports.
9 Previous studies debating whether aid leads to trade (the basis for tying aid) or whether causality runs in the other
direction find more evidence for the latter case (Osei, Morrissey, and Lloyd 2004; Lloyd et al. 2000).
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The second measure, Export, captures the importance of the donor as an important
export destination for the recipient, and thus reflects the recipient’s trade interests. It is the share
of a recipient’s total exports that flows to the donor:
!
Exportdrt =Exportdrt
Total Exportrt,
where Exportdrt is the recipient’s exports to the donor in year t and Total Exportrt is the
recipient’s total exports for that year. If market access and aid are substitutes, then this measure
of bilateral trade ties will have a negative impact on aid flows, and
!
"2 will be negative. Donors
that have small foreign aid budgets, such as the United Kingdom, are more likely to adopt this
aid allocation strategy. Note that in considering market access and aid as substitutes, the donor is
taking into account the recipient’s perspective by considering whether the donor is an income
source for the recipient country.
The specification in equation (1) assumes that donors base their aid allocation decisions
for year t on trade data for only the previous year. A priori, we can’t rule out the possibility that
historical trade relationships spanning a longer time horizon also matter: trade relationships may
differ from one political regime to another if one government regime is more open to trade than
another. Indeed in their study of politically motivated foreign aid Faye and Niehaus (2010) find
that regimes that are more politically aligned with the five largest bilateral donors receive more
aid from these donors.
To account for the possibility that regimes are important, for each of the two trade
measures discussed I calculate the bilateral trade ties over two time horizons: (i) a year-to-year
measure already described; and (ii) a regime-specific measure where a regime indicates the
period over which a single head of state is in power. For each year, I calculate the cumulative
bilateral trade ties starting from a recipient country regime’s first year in power.10 I use data
from the World Bank’s DPI (2009) to identify the length of time a single head of state (regime)
is in power in the recipient country. I test the baseline model using both the year-to-year and
regime-specific measures of donor’s bilateral trade ties listed above. The regime-specific
bilateral trade measure captures the idea that the head of state matters (Fisman 2001), with some
10 All trade figures are deflated to constant 2000 US dollars using the donor’s GDP deflator for the Trade share
variable, and using the recipient’s GDP deflator for the Export share variable.
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regimes being more open to trade than others. We can reinterpret the discussion above in terms
of whether donors with larger trade ties to regimes see bigger or smaller foreign aid flows, and
whether regimes that export more to a donor country receive more or less aid.
If regimes are important, then donors will also care about elections. There are several
reasons to expect aid commitments during election years to be different than those observed in
non-election years. Faye and Niehaus (2010) show that donors give more aid to closely aligned
regimes facing competitive elections, and argue that the donor may try to influence the election
probabilities. On the flip side, if the government in power in the aid recipient country is not
aligned with the donor in terms of political or economic interests, the donor may withhold aid or
impose increased conditionality on aid to hamper that regime’s chances of winning the elections.
But donors could also scale back foreign aid commitments ahead of elections if they fear the
recipient government will divert funds from donor-prioritized investment projects to more
conspicuous consumption spending such as roads or food subsidies. Regimes that enjoy close
economic and political ties with donor governments may see a smaller or no decrease in aid. Of
course there are other reasons for expecting election year changes in foreign aid flows. Donors
claim that they reward countries with more democratic institutions. To the extent that having
elections signals a more democratic regime, the effect of an election event on foreign aid should
be positive.
In the next set of regressions, I look at differences in election year effects between donor
and recipient pairs on the basis of their trade ties. I extend the baseline model to include political
variables, and test for the effects of elections and political competitiveness by using an empirical
strategy similar to a difference-in-difference estimate:
!
ODAdrt = "1Tradedrt#1
+ "2Exportdrt#1
+ "3EXECrt + "
4EXECrt $Tradedrt#1
+ "5EXECrt $ Exportdrt#1
+ "6PCOMP + "
7PCOMP $ EXECrt
+ "8PCOMP $Tradedrt#1
+ "9EXECrt $PCOMP $Tradedrt#1
+ "10PCOMP $ Exportdrt#1
+ "11EXECrt $PCOMP $ Exportdrt#1
!
+ " X drt#1
b + µrt
+ $drt
(2)
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where EXECrt is an indicator variable that takes a value of 1 during an election year in the
recipient country and is 0 otherwise,11 and PCOMPrt-1 is an indicator variable for political
competition in the recipient country. I follow Block (2002) and construct the political
competitiveness variable from two electoral competition variables in the DPI 2009 dataset, the
Legislative Indicator of Electoral Competition (LIEC) and the Electoral Indicator of Electoral
Competition (EIEC). The DPI (2009) ranks competitiveness on a scale of 1 to 7 as described in
Table 4, with 1 being not competitive. PCOMPrt-1 is equal to 1 if the score on either the EIEC or
the LIEC measure is 6 or higher, and it is 0 otherwise. Table 5 presents the number of elections
year events faced by each donor for the in-sample dataset, and the numbers are further broken
down by whether the regimes are politically competitive or not. Election year events represent
roughly 10 per cent of the observations for each donor.
The signs of the coefficients in equation (2) are difficult to predict. Aid ahead of
elections may be increased or decreased depending on whether a donor favours the incumbent
party, or whether the donor wants to support the electoral process in general. If donors indeed
reward democracy, then the coefficient on political competition, and possibly its interactions,
will be positive.
One concern with the specifications above is the presence of some time invariant donor
specific, recipient specific, or a donor-recipient pair specific bilateral relationship that determines
the level of aid flows. Previous studies have shown that bilateral relationships such as a common
language and former colonial ties (Rajan and Subramanian 2008), or strategic alliances as in the
case of the United States with Israel and Egypt (Kuziemko and Werker 2006), are good
predictors of aid flows. Separating the donor-recipient fixed effects (!dr) from the time varying
component of the error term (!drt) alleviates this concern, and I can use the time varying trade,
election and other control variables to study the time varying component of foreign aid flows.
A second concern is the pooling of all the donors into one fixed effects estimation, as this
measures the average of different aid-giving strategies by different donors. The size of the
dataset allows me to run the estimation described above for each donor separately with recipient
fixed effects, time fixed effects and time trends. I can therefore compare the United States’ aid-
giving behaviour to that of the United Kingdom or Japan. In these estimations, the unit of
11 These are executive elections only, and do not include legislative elections.
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observation is a recipient-year pair and I use recipient fixed effects to capture the time invariant
determinant of foreign aid flows.
Finally, Xdrt-1 is a vector of time varying donor- or recipient-specific demographic control
variables consisting of both donor and recipient GDP and population and recipient country infant
mortality.
4 Results
4.1 Are donor and recipient trade interests associated with ODA
commitments?
In the baseline model given by Equation (1), I test the effect of the donor’s bilateral trade
ties and recipient's export share on foreign aid flows using a pooled panel dataset with the five
largest donors: France, Germany, Japan, the United Kingdom and the United States. Recall that
Tradedrt measures the share of the donor’s total trade with the recipient. If donors tie aid to trade,
then we should expect to see aid positively related to donor-recipient trade ties. If trade and aid
are substitutes, then we should see a negative relationship. Moreover, if donors substitute market
access with aid, then the coefficient on recipients' Export share to the donor will be negative.
However, each donor may have a different aid giving strategy and it is difficult to predict the
signs of the coefficients on donor and recipient trade interests,
!
"1 and
!
"2 respectively.
Table 6 presents the results for the baseline estimation with both the year-to-year and the
regime-specific measures. All columns have donor-recipient pair fixed effects and accordingly
clustered robust standard errors. They also contain the full set of demographic controls for both
donors and recipients.12 The coefficient on the Trade variable is positive, but just significant at
the 10 per cent level and only for the Year-to-Year measure in the regression with time fixed
effects in Column (2). The coefficient on the Export variable is not significant at all. In a panel
of five donors, increased Trade ties with a recipient are weakly associated with higher ODA
flows, but recipient Export shares are not important.
Turning towards the demographic characteristics, recipients with higher real GDP receive
less aid. This is consistent with at least one of the elements of poverty targeting strategies and
12 In the interest of clarity I do not report the fixed effects estimation without controls.
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what we would expect of aid recipient characteristics. Also in keeping with intuition, donors
with higher incomes give more aid. However, the coefficient on infant morality is not significant
or positive as expected, though it may be negatively associated with recipient GDP. Finally,
neither donor nor recipient population size are systematically associated with foreign aid
commitments.
4.2 Do donors differ in ODA allocation strategies?
I now turn to assessing the aid allocation strategies of individual donors. The results
above imply that all five donors in the pooled estimation behave in the same way on average. In
particular, the pooled regression results in Table 6 suggest that Trade is only weakly associated
with ODA commitments from France, Germany, Japan, United Kingdom and the United States.
The results also suggest that there is no relationship between Export shares and ODA
commitments from these donors. But as explained before, pooling the donors together can mask
donor-specific effects.13 If one donor exhibits a positive relationship between aid and Export
while another donor has a negative relationship, these two effects may cancel each other out in
the pooled estimation. It may also be the case that the results observed are driven by one or two
donors in the pool. In the first instance we would incorrectly infer that there is no relationship
between ODA commitments and bilateral trade ties for any of the donors, and in the second
instance we would incorrectly infer that all five donors exhibit the observed relationship. The
purpose of the following set of regressions is to disentangle any such opposing effects.
Table 7 presents the estimation results for equation (1) for each separate donor. I focus
on the regime-specific measures here to keep the discussion tractable. All columns contain
recipient fixed effects, and the even numbered columns also contain year fixed effects. While all
columns contain donor and recipient demographic controls, smoothed real GDP and populations
using logs for France, Germany, UK and USA cause collinearities with year dummies and the
regression drops the Donor Real GDP and Donor Population variables.
The results indicate that the positive coefficient on the Trade variable earlier was being
driven by the positive relationship for the US. United Kingdom exhibits a negative relationship
13 See Osei, Morrissey, and Lloyd (2004) for a discussion on problems with pooled data. While they also stress that
pooling recipients is a problem, I try to identify differences in recipient characteristic that relate to systematic
differences in ODA commitments.
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between Trade and ODA. However, this effect is lost in the pooled estimation as the volume of
ODA flows from the US is typically about fives times that of the UK. Thus the US gives higher
ODA commitments to countries with which it trades more, whereas the UK pledges decreased
aid commitments to countries with which it trades more. The relationship between Export share
and ODA commitments is positive and large relative to the standard errors for Japan and UK,
although it is only significant at the 10 per cent level for Japan in the specification without year
fixed effects in Column (5). Therefore countries that send a higher share of their exports to
Japan receive higher ODA commitments.
ODA commitments are not related to bilateral trade ties for either France or Germany.
Past studies have found that donors generally give more aid to former colonies, and this is
especially true for France (Rajan and Subramanian 2008). If France trades more with former
colonies, then we would expect to see a positive relationship between aid and bilateral trade ties.
In that case the reason we don’t see this effect in the results may be owing to the recipient fixed
effects picking up any effect of colonial ties.
There are also variations from the pooled estimate for the demographic controls. The
negative relationship between ODA commitments and recipient real GDP no longer hold for
Germany and Japan. Increases in recipient population size are associated with lower ODA
commitments from France but larger commitments from the US. Surprisingly, France's ODA
commitments decrease as its real GDP increases. Increases in donor population are related to
higher ODA commitments from France and Japan, and lower commitments from Germany and
the US.
Thus donors differ not only in how their aid allocation relates to trade interests, but also
in the association of aid with donor and recipient income and populations. Given the differences
in donor aid allocation, I focus on a disaggregated analysis of donors in the next two sections.
4.3 Do ODA commitments differ during election years?
So far the analysis has focused on the relationship between aid allocation and trade
interests, and the importance of distinguishing between aid allocation strategies of different
donors. From this point onwards, I look at whether political factors, in addition to trade interests,
are important in shaping foreign aid flows. Elections can matter for several reasons as discussed
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before. With a reduced tolerance towards aid fungibility and the emphasis on conditionality,
donors may fear that recipient countries will misspend aid money or ignore donor-priorities
ahead of elections, and instead focus on visible fiscal spending to boost their chances of winning
the election14. This is of particular concern in countries with weak institutional constraints (Shi
and Svensson 2002). Consequently donors may cut aid commitments ahead of elections. On
the other hand, if donors care about the government regimes holding power in recipient
countries, they may have an interest in election outcomes. To the extent that donors believe
ODA flows can help or hinder election results, and if they further want to affect election
outcomes, donors may withhold or augment foreign aid flows ahead of elections.
In order to test whether election events are important for donors I test whether aid
allocation is different in election years compared to non-election years in recipient countries. I
further ask whether donors distinguish between recipients in whom they have greater trade
interests and recipients for whom they form a larger export market. To this end I estimate a
reduced form of equation (2) given by
!
ODAdrt = "1Tradedrt#1
+ "2Exportdrt#1
+ "3EXECrt + "
4EXECrt $Tradedrt#1
+ "5EXECrt $ Exportdrt#1
+ % X drt#1b + µrt + &drt
, (3)
where
!
"4 and
!
"5, the coefficients on the interaction terms, capture the differential effect of
elections on ODA commitments for the closer trade partners. Table 8 presents the results for the
five donors using the regime-specific measures of Trade and Export.
While the coefficient on the EXEC elections dummy,
!
"3, is not significant, some of the
interaction terms are significant. There are no election year effects for France and Japan, and the
results do not change from the estimation without elections. For Germany,
!
"4
< 0 and
significant at the 1 per cent level, indicating that during election years countries with which
Germany trades more receive lower ODA commitments. The Trade variable in both Columns
(7) and (8) for the UK is now negative and significant, compared to just Column (8) of Table 7 in
the previous section. In addition, the interaction of elections with Export share is negative
!
"5
< 0
and significant at the 10 per cent level, indicating that countries that export more to the UK can
14 Schuknecht (2000) finds that expansionary fiscal policies ahead of elections are mainly due to increased spending
rather than lower revenues.
16
expect to see a fall in ODA commitments during election years. The Trade, Export and election
variables however fail the test of joint significance, but just barely in the estimation with year
fixed effects (p-value = 0.105). Finally, the Trade variable is still positive and significant for
the US, but in addition during election years countries with which the US trades more see a
decrease in foreign aid commitments
!
("4
< 0) . This last result is significant only for the
estimation without year fixed effects in Column (9) and then only at the 10 per cent level.
Moreover, the Trade, Export and election variables fail the test of joint significance (p-value =
0.376). Adding year fixed effects in Column (10) however makes these variables jointly
significant (p-value = 0.053).
The results in this section thus indicate the presence of election year cycles in ODA
commitments for some of the donors, namely Germany, the UK and the US. It is difficult
however to be able to say anything about the motivations behind these cycles. In other words, if
a donor cuts aid allocation during election years, is it because the donor anticipates misuse of
funds or because it does not want to enhance the incumbent government's probability of winning
the election, or is such behaviour perhaps motivated by some other reason? Moreover, are
elections in countries with a de facto democratic system viewed in the same light as elections in
countries that are merely democracies de jure where elections don't matter? If not, then donors
may have different aid allocation strategies for countries with politically competitive and those
with non-competitive electoral processes, and I investigate this angle in the next section.
4.4 Do ODA commitments differ for politically competitive regimes?
In this section I look at whether political competitiveness of recipient regimes matters for
aid allocation, and whether donors treat politically competitive election years differently than
non-competitive ones. If donors fear misuse of funds, then it is worthwhile to note that political
budget cycles marked by increases in fiscal spending are exacerbated ahead of closely contested
elections (Block 2002). On the other hand, Faye and Niehaus (2010) suggest that the US plays a
more active role in politically competitive elections by increasing aid flows to regimes with
which they are more politically aligned to influence election outcomes.
The results in the previous sections suggest that the aid allocation strategies of some
donors are sensitive to regime-specific trade relationships and to election years. If a donor with a
17
positive aid-trade relationship fears misallocation of aid money and cuts aid ahead of elections, it
will likely cut less for the regimes with close trade ties. If it is trying to influence elections, it
should increase aid to closer trading partners facing politically competitive elections. Donors
claim that they reward more democratic countries with more aid, thus more politically
competitive regimes should also see increased foreign aid commitments.
I test the effect of election and political competitiveness in the framework of donor and
recipient trade interests by estimating equation (2). While the purpose of this exercise is to
identify differences in aid allocation strategies when present across donors, I first report the
results of the pooled panel of donors to serve as a benchmark.
Table 9 presents the results of the pooled estimate for both the year-to-year and regime-
specific measures. As before (Table 6), Trade is positively associated with ODA commitments
but is significant only for the year-to-year measure run with year fixed effects in Column (2); and
the coefficient on Export is not significant. However this is the case for the non-competitive
regimes in the estimation of equation (2). We further see that for non-competitive regimes,
donors decrease aid flows during election years for close Trade partners
!
"4
< 0( ) , but regimes
that export more to the donor countries can expect to see an increase in ODA commitments
!
"5
> 0( ) . The last result is significant only with the year-to-year measure.
Politically competitive regimes receive higher ODA commitments than non-competitive
regimes
!
"6
> 0( ) , and experience no election year effects
!
"7
= 0( ) unless mediated by donor or
recipient trade interests. There is no additional effect of political competitiveness on ODA
commitments for countries with which the donors trade more
!
"8
= 0( ) , but there is a differential
positive effect on ODA commitments for these countries during election years
!
"9
> 0( ) . For
countries that trade more, the total effect of elections on politically competitive countries is given
by
!
"4
+ "9. While this may be positive, zero or even negative, any negative effect of elections on
ODA commitments will still be necessarily less for politically competitive countries than the
negative effect faced by non-competitive countries during election years15. Finally politically
competitive countries with larger Export shares receive higher aid commitments
!
"10
> 0( ) but
there is an additional negative effect during election years
!
"11
< 0( ) . Relative to their non-
15 Since
!
"9
> 0 ,
!
"4
+ "9
> "4
.
18
competitive counterparts who receive higher commitments during election year, all else equal
politically competitive regimes see no such change
!
"5
+ "11( ) .
Next, I run identical estimations testing differential effects of elections and trade by
political competitiveness for each of the five donors: France, Germany, Japan, UK and USA.
To keep the discussion tractable I summarize the results for these estimations using the regime-
specific measures of Trade and Export in Table 10, presenting only the signs of the coefficients
under investigation and their significance16. To allow for easier comparison, I also include the
summarized results from Columns (3) and (4) of Table 9 for the pooled panel discussed above.
As expected, individual donor behaviours are either muted or driven by only a subset of
the donors in the pooled estimation. Mirroring the pooled regression result however, neither the
elections dummy by itself nor its interaction with the political competitiveness indicator is
related to foreign aid flows for any of the donors. The positive coefficient for political
competitiveness seen in the pooled regression reflects the behaviour of only some of the donors:
Germany, Japan and the UK favour political competitiveness
!
"6
> 0( ) . The donors otherwise
exhibit very different aid allocation behaviours, and for the remainder of the section I will
document these behaviours.
France
None of the economic or political variables or their interactions is significant for France.
As was mentioned before, France's aid allocation strategies may be driven for the most part by
links to its former colonies and the recipient country fixed effects used in the empirical model
should capture this effect.
Germany
ODA commitments from Germany are positively associated with political
competitiveness. Thus a country that has a competitive electoral system will receive larger aid
commitments on average than one with a non-competitive regime. Germany also exhibits a
weak election year effect, with ODA commitments to non-competitive regimes with which it
16 See Tables B1 through B5 in Appendix B for the regression results for France, Germany, Japan, UK and USA.
19
trades more falling during election years
!
"4
< 0( ) . There are no differential effects for politically
competitive regimes beyond that given by
!
"6.
Japan
Japan too favours political competitiveness
!
"6
> 0( ) . However, if Japan trades more with
these politically competitive countries, the latter can expect to see a decrease in ODA
commitments
!
"8
< 0( ) . Together this suggests that for politically competitive countries, Japan
treats trade and aid as substitutes. While the remainder of the interactions don't have significant
coefficients, tests of linear combinations of the trade and political variables and their interactions
reveal other nuances in Japan's aid allocation behaviour.
Table 11 reports the signs and levels of significance for the tests of linear combinations
of the relevant interactions and correspond to the regressions summarized in Table 10. Even
though the coefficient on Exports,
!
"2, and none of its interaction terms are significant, linear
combination of coefficients given by Export + PCOMP*Export
!
"2
+ "10( ) is positive and
significant for the estimation without year fixed effects. Thus politically competitive countries
that export more to Japan receive higher aid commitments. Moreover, the additional effect of
having elections, given by the linear combination (10)
!
"5
+ "11
< 0( ), is negative and indicates
that these countries see a cut in foreign aid during election years. Thus Japan exhibits election
year cycles in foreign aid commitments.
Note that the effects of Trade and Export interacted with political competitiveness go in
opposite directions, with politically competitive countries that Trade more receiving lower aid
commitments. This suggests that Japan differentiates between its exports and imports when
considering foreign aid allocation decisions.
United Kingdom
Table 10 shows that the UK gives more aid to politically competitive countries than non-
competitive countries
!
"6
> 0( ) . Similar to the case of Japan, politically competitive regimes with
which the UK trades more see lower aid commitments
!
"8
< 0( ) . Thus the UK too treats trade and
aid as substitutes for politically competitive countries. The additional effect of having elections
for politically competitive countries is positive
!
"9
> 0( ) . Table 11 indicates that despite total
20
positive effect of elections on ODA commitments
!
"4
+ "9
> 0( ) , the negative interaction of
political competitiveness with Trade
!
"8
< 0( ) implies that ODA commitments for politically
competitive countries that trade more with the UK still fall during election years
!
"1
+ "4
+ "8
+ "9
< 0( ) . This decrease however is less than that during non-election years.
Finally, politically competitive countries that export more to the UK see increases in
ODA commitments
!
"10
> 0( ) . Thus UK too appears to distinguish between its imports and
exports with relation to ODA allocation decisions.
Trade share and Export share don't affect ODA allocation to non-competitive countries
for the UK. Nor do non-competitive countries experience election year changes in ODA
commitments.
United States of America
In contrast to Germany, Japan and the UK, the US does not give more aid to countries
with competitive electoral systems. Instead it increases ODA commitments to non-competitive
regimes with which it trades more
!
"1
> 0( ) . While the additional impact of political
competitiveness is negative
!
"8
< 0( ) , the test of linear combination in Column (5) of Table 11
reveals that there is no overall association between trade and ODA commitments for politically
competitive countries
!
"1
+ "8
= 0( ) . The US also exhibits additional election year effects. ODA
commitments to non-competitive regimes with which it trades more fall during election years
!
"4
< 0( ) , though politically competitive regimes see no such decrease
!
"4
+ "9
= 0( ) .
Next, the non-competitive regimes that export more to the US receive less foreign aid
!
"2
< 0( ) , suggesting that the US uses market access and aid as substitutes. This effect disappears
during election years
!
"2
+ "5
= 0( ). Although the additional effect of political competitiveness on
countries exporting more to the US is positive
!
"10
> 0( ) , the ODA commitments to politically
competitive regimes US are unaffected by exports
!
"2
+ "10
= 0( ) .
Thus the US shows election year cycles in ODA allocation. In general it allocates more
aid to non-competitive regimes with which it trades more, but cuts their aid during election
years. The US also treats market access and aid as substitutes for non-competitive countries, but
this substitution effect disappears during election years.
21
5 Robustness
The bulk of the analysis thus far has focused on the relationship between ODA
commitments and donor and recipient trade interests using the regime-specific measures for the
Trade and Export variables. However, I also run the same estimations using the more
conventional year-to-year measures described before. While the differences in trade and export
shares calculated using the year-to-year measure is typically small, especially for regimes with
shorter time spans, the difference can increase for longer lasting regimes. We would expect
ODA allocation behaviour to be different for the year-to-year measure if a donor responds more
to recent (previous year) changes than changes in the general orientation of bilateral trade ties of
the regime.
Table 9 already reported the results for the estimation of equation (2) for both the year-to-
year and regime-specific measures for the pooled panel of donors. Tables B1 through B5 in
Appendix B report the corresponding results for the five bilateral donors: France, Germany,
Japan, the UK and the US. The central results for the year-to-year estimation remain unaltered
from those of the regime-specific estimation for the most part. The two notable differences are
in the case of France and Germany.
Recall that France showed no relationship between ODA commitments and any of the
Trade, Export, election or political competitiveness variables and their interactions. With the
year-to-year measure however, the coefficient on the interaction term PCOMP*Export becomes
more negative and acquires significance. Thus for politically competitive countries, France now
treats market access and ODA as substitutes. The trade and political variables however fail the
test of joint significance in both cases (p-values are 0.618 and 0.125).
In Germany's case, using the year-to-year measures of trade ties causes the coefficients
on the interaction terms for EXEC*Trade to become significant for the specification with fixed
effects as well17. Another change is that the coefficient on the interaction term EXEC*Export
increases in magnitude and, for the specification with year fixed effects, becomes significant at
the ten per cent level. Thus during election years Germany lowers ODA commitments to
17 Using the regime-specific measure the coefficient was significant only for the specification without year fixed
effects. The sign is consistently negative throughout.
22
countries with which it trades more, but increases its aid commitments to countries which send a
greater share of their exports to Germany.
6 Summary and Discussion
Using a panel dataset of five aid donors and over a hundred recipients, I document
several empirical relationships between donors' ODA commitments and their regime-based
bilateral trade ties with aid recipient countries. I demonstrate that the nature of these
relationships varies from donor to donor, and that donors exhibit election year cycles in ODA
commitments. I further demonstrate that donors distinguish between countries that have
politically competitive electoral systems and those that do not.
Germany showed a positive association between political competitiveness by itself and
ODA commitments. Germany cuts aid to non-competitive regimes during election years, and
this result is stronger for the year-to-year measure. Using this measure I also find that countries
that export more to Germany experience an increase in ODA commitments during election years.
Japan and the UK also favour politically competitive regimes, but give less aid to these countries
if they account for a larger share of total trade with the respective donor. Thus trade and aid
appear to be substitutes in the case of politically competitive recipients. However, this
substitution of trade with aid is mitigated during election years for UK aid recipients. Both
countries also reward countries that export more to them with higher ODA commitments, but
Japan cuts aid to these countries during election years.
Finally the US pledges more aid to non-competitive regimes with which it trades more
but cuts their aid during election years. It also treats market access and aid as substitutes for
non-competitive regimes. During election years however, countries that export more to the US
do not see this substitution effect and so don't experience the decrease in aid as in non-election
years. ODA flows to politically competitive regimes are not associated with trade relationships
or election year events for the United States.
France is the only country in the study for which there was no relationship between ODA
commitments and regime-specific trade or political variables. With the year-to-year measure of
trade ties however, France treats aid and the market access as substitutes, but only for politically
competitive countries.
23
The goal of this study was to establish some empirical links between aid flows and
interests other than poverty reduction in order to inform the aid effectiveness debate. To this end
I demonstrated how donor trade interests, election events and political competitiveness of
recipient countries are associated with foreign aid commitments from the five largest bilateral aid
donors in the OECD's DAC. Some aid allocation strategies such as substituting aid for market
access and rewarding political competitiveness appears reasonable in supporting development
goals. The implications for development of other strategies are not so clear, for instance the US'
giving more aid to countries with non-competitive regimes if they are larger trading partners.
Along with Germany, Japan and the UK, it also exhibits political aid cycles around election
years. It is difficult to ascertain whether such responses in foreign aid flows help or hinder
economic development. Donor governments may after all be trying to either influence election
outcomes so that a better leader comes to power, or trying to ensure that aid money is not mis-
spent by cutting aid during election years. On the other hand, donors may be strategic about
their own interests.
Further work needs to be done to identify the political and non-political motivations that
drive foreign aid flows. For instance, using closeness of elections as a measure for political
competitiveness will better identify instances of when the donor tries to influence the election
outcome. A measure of the electoral process better proxies a country's degree of democracy and
can be used to gauge whether donors reward democracy. Another venue of research is to explore
the motivations of multilateral aid flows. While multilateral aid is considered to be more in line
with poverty-targeting, the biggest financiers of multilateral aid organisations are the bilateral
donors, and it will be informative to test whether multilateral aid is also influenced, at least in
part, by donors' political motivations and if they exhibit election year cycles.
It is important that any study on aid effectiveness should account for the different
purposes of foreign aid. Assuming all foreign aid flows are for development purposes when it is
not will no doubt show that aid is ineffective. Understanding the donor driven political and
economic motivations behind foreign aid allocation will prepare policymakers in reforming the
foreign aid process, with the hope that it will eventually help identify effective and non-effective
channels of aid.
24
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26
Appendix A Data Summary and Results
Table 1 List of Recipient Countries
Albania Guinea-Bissau Saudi Arabia
Algeria Guyana Senegal Armenia Haiti Sierra Leone
Azerbaijan Honduras Slovenia
Bahrain India South Africa Bangladesh Indonesia Sri Lanka
Barbados Iran St. Lucia
Belize Israel Sudan Benin Jamaica Syria
Bolivia Jordan Tajikistan
Bosnia-Herzegovina Kazakhstan Tanzania
Brunei Kenya Thailand Burkina Faso Korea Togo
Burundi Kuwait Trinidad and Tobago
Cambodia Kyrgyz Republic Tunisia Cameroon Laos Turkey
Cape Verde Lebanon Turkmenistan
Central African Republic Macedonia, FYR Uganda Chad Malawi United Arab Emirates
Chile Malaysia Uruguay
China Maldives Uzbekistan
Colombia Mali Venezuela Comoros Malta Yemen
Congo, Republic Mauritania Zambia
Costa Rica Mauritius Zimbabwe Cote d'Ivoire Mexico
Croatia Moldova
Cyprus Mongolia
Djibouti Morocco Dominican Republic Mozambique
Ecuador Nepal
Egypt Niger El Salvador Nigeria
Ethiopia Oman
Gabon Pakistan Gambia Panama
Georgia Papua New Guinea
Grenada Paraguay
Guatemala Philippines Guinea Rwanda
27
Figure 1 ODA Commitments by Donor Type (1975 – 2007)
Source: OECD (2009)
Figure 2 Share of Total DAC ODA Commitments (1975 – 2007)
Source: OECD (2009)
28
Table 2 Variable Description and Sources
Variable Description Sources
ODA Log of annual ODA total commitments - grants and
loans (constant 2000 US$ millions) OECD (2009)
Trade Lagged volume of donor-recipient trade as share of
total donor trade (%) IMF DOTS (2010)
Export Lagged volume of recipient exports to donor as share
of total recipient exports (%) IMF DOTS (2010)
EXEC Dummy variable for executive elections in recipient
country (= 1 for election year and 0 otherwise) World Bank DPI (2009)
PCOMP
Dummy variable for political competitiveness of the electoral process (= 1 for competitive process and 0
otherwise)
World Bank DPI (2009)
Real GDP Lagged log of Gross Domestic Product of recipient
(constant 2000 $US millions) World Bank WDI (2010)
Pop Lagged recipient population (millions) World Bank WDI (2010)
Infant Mortality Lagged infant mortality (deaths per 1000 births) World Bank WDI (2010)
Donor Real GDP Lagged donor Gross Domestic Product of trading
partner (constant 2000 $US millions) World Bank WDI (2010)
Donor Pop Donor population (millions) World Bank WDI (2010)
29
Table 3 Summary Statistics by Donor
Variable N Mean St. Dev Min Max
Pooled
ODA commitments 12335 65.29 251.53 0.01 15161.08
Donor Trade Share, Year-to-Year 12335 0.16 0.62 0 14.39
Donor Trade share, Regime-specific 12335 0.16 0.57 0 13.62
Recipient Export share, Year-to-Year 12335 5.92 9.80 0 115.16
Recipient Export share, Regime-specific 12335 6.24 9.61 0 83.09
USA
ODA commitments 2320 108.35 429.28 0.01 15161.08
Donor Trade Share, Year-to-Year 2320 0.21 0.84 0 9.96
Donor Trade share, Regime-specific 2320 0.20 0.78 0 9.96
Recipient Export share, Year-to-Year 2320 12.45 15.55 0 115.16 Recipient Export share, Regime-specific 2320 12.45 14.66 0 83.09
France
ODA commitments
2516 35.58 74.59 0.01 1328.69
Donor Trade Share, Year-to-Year 2516 0.12 0.26 0 4.51
Donor Trade share, Regime-specific 2516 0.12 0.25 0 3.22
Recipient Export share, Year-to-Year 2516 4.62 7.48 0 69.69
Recipient Export share, Regime-specific 2516 5.11 7.79 0 69.69
Germany ODA commitments 2718 38.39 77.42 0.01 1290.04
Donor Trade Share, Year-to-Year 2718 0.10 0.22 0 3.12
Donor Trade share, Regime-specific 2718 0.10 0.20 0 2.88
Recipient Export share, Year-to-Year 2718 4.15 5.23 0 64.88
Recipient Export share, Regime-specific 2718 4.27 4.71 0 64.88
Japan
ODA commitments 2663 116.13 329.21 0.01 4881.22
Donor Trade Share, Year-to-Year 2663 0.30 0.99 0 14.39
Donor Trade share, Regime-specific 2663 0.30 0.92 0 13.62
Recipient Export share, Year-to-Year 2663 4.50 8.35 0 98.78
Recipient Export share, Regime-specific 2663 4.71 8.28 0 76.39
UK
ODA commitments 2118 24.01 84.80 0.01 2250.65
Donor Trade Share, Year-to-Year 2118 0.07 0.17 0 2.03
Donor Trade share, Regime-specific 2118 0.08 0.17 0 2.03
Recipient Export share, Year-to-Year 2118 4.34 6.86 0 55.35
Recipient Export share, Regime-specific 2118 5.22 7.95 0 55.88
NOTE. ODA commitments are in millions of constant 2007 US dollars. Trade and Export shares are in
percentages.
30
Table 4 Legislative and Executive Indices of Electoral Competition
Criteria Score
No legislature 1
Unelected legislature 2
Elected legislature, 1 candidate 3
Elected legislature, 1 party, multiple candidates 4
Multiple parties are legal, but only one party won seats 5
Multiple parties did win seats but the largest party received more than 75% of the seats 6 Largest party got less than 75% of the seats. 7
Source: Reproduced from Keefer (2009)
Table 5 Incidence of Elections by Donor and Political Competitiveness
Political Election Year
Donor Competitiveness No Yes N
Non-Competitive 720 76
Competitive 1506 214 France
All 2226 290 2516
Non-Competitive 809 83 Competitive 1603 223 Germany
All 2412 306 2718
Non-Competitive 787 82
Competitive 1573 221 Japan
All 2360 303 2663
Non-Competitive 583 72
Competitive 1280 183 UK
All 1863 255 2118
Non-Competitive 631 73
Competitive 1410 206 USA
All 2041 279 2320
31
Table 6 Pooled ODA Commitments, Donor Bilateral Trade Ties and Recipient Export Shares
1975-2008
Dependent variable is log ODA commitments
Year-to-Year Regime-Specific
(1) (2) (3) (4)
Tradet-1 0.059 0.113* 0.060 0.095
(0.061) (0.068) (0.071) (0.074)
Exportt-1 0.004 0.002 0.008 0.005
(0.004) (0.004) (0.006) (0.006)
Real GDPt-1 -0.029 -0.053*** -0.030 -0.053***
(0.019) (0.020) (0.019) (0.020)
Popt-1 -0.327 0.500 -0.298 0.485 (0.242) (0.352) (0.244) (0.352)
Infant Mortt-1 -0.001 -0.001 -0.001 -0.001
(0.001) (0.002) (0.001) (0.002)
Donor Real GDPt-1 0.429*** 0.804*** 0.425*** 0.794***
(0.096) (0.135) (0.097) (0.136)
Donor Pop -1.066 0.315 -1.072 0.285
(1.046) (1.120) (1.050) (1.123)
Year -0.030*** -0.028**
(0.011) (0.011)
Year FE's N Y N Y
Observations 12370 12370 12335 12335
R-squared 0.012 0.037 0.012 0.037
Number of donor-recipient pairs 501 501 501 501
Model F (p-value) 0.000 0.000 0.000 0.000
Joint F (p-value) 0.247 0.180 0.162 0.228
NOTE. FE = fixed effects. All regressions are FE estimations. All columns include country fixed effects. Year
dummies are not shown. P-values are reported for the test of joint significance of bilateral Trade Share and Export
Share variables. Robust standard errors are in parentheses and clustered at donor-recipient pairs, *** p<0.01, **
p<0.05, * p<0.10.
32
Table 7
ODA Commitments, Donor Bilateral Trade Ties and Recipient Export Shares by Donor
1975-2008
Regime-Specific
Dependent variable is log ODA commitments
FRA DEU Japan UK USA
(1) (2) (3) (4) (5) (6) (7) (8) (9) (10)
Tradet-1 0.066 0.066 0.098 0.194 -0.019 0.007 -0.760 -0.889* 0.293* 0.300**
(0.176) (0.186) (0.376) (0.397) (0.100) (0.099) (0.478) (0.490) (0.156) (0.117)
Exportt-1 0.007 0.007 -0.006 -0.009 0.027** 0.020 0.027 0.025 -0.001 -0.005
(0.009) (0.008) (0.010) (0.010) (0.012) (0.013) (0.018) (0.018) (0.008) (0.007)
Real GDPt-1 -0.062* -0.072** -0.036 -0.040 0.066 0.045 -0.084* -0.081* -0.090** -0.134***
(0.032) (0.035) (0.031) (0.034) (0.051) (0.051) (0.048) (0.046) (0.037) (0.040)
Popt-1 -1.026** -0.797 0.239 0.528 -0.679 -0.050 0.138 0.394 1.551 2.332**
(0.505) (0.569) (0.462) (0.612) (0.576) (0.679) (0.641) (0.795) (1.003) (1.121)
Infant Mortt-1 -0.002 -0.002 -0.002 -0.003 -0.003 -0.003 0.001 -0.001 0.001 0.002
(0.003) (0.003) (0.003) (0.003) (0.004) (0.004) (0.003) (0.004) (0.004) (0.004)
Donor Real GDPt-1 -0.367*** 0.000 0.574*** 0.000 0.268 0.840*** 0.599*** 0.000 4.378*** 0.000
(0.137) (0.000) (0.113) (0.000) (0.189) (0.298) (0.223) (0.000) (1.052) (0.000)
Donor Pop 5.932** 0.000 -21.294*** 0.000 9.723** 0.000 -7.027 0.000 -16.356*** 0.000
(2.969) (0.000) (2.804) (0.000) (4.325) (0.000) (7.296) (0.000) (3.221) (0.000)
Year 0.013 -0.017 0.009 -0.027 -0.033
(0.015) (0.015) (0.023) (0.025) (0.030)
Year FE's N Y N Y N Y N Y N Y
Observations 2516 2516 2718 2718 2663 2663 2118 2118 2320 2320
R-squared 0.022 0.043 0.077 0.092 0.084 0.102 0.023 0.051 0.034 0.146
Number of recipients 103 103 105 105 104 104 92 92 97 97
Model F (p-value) 0.020 0.000 0.000 0.000 0.000 0.000 0.003 0.000 0.000 0.000
Joint F (p-value) 0.673 0.654 0.813 0.626 0.0972 0.328 0.132 0.103 0.147 0.0390
NOTE. FE = fixed effects. All regressions are FE estimations. Donor and recipient Real GDP and Population variables are in logs. All columns include country
fixed effects. Year dummies are not shown. P-values are reported for the test of joint significance of bilateral Trade Share and Export Share variables. Robust
standard errors are in parentheses and clustered at recipients, *** p<0.01, ** p<0.05, * p<0.10.
33
Table 8
Election Year Differences in ODA Commitments by Donor
1975-2008
Regime-Specific
Dependent variable is log ODA commitments
France Germany Japan UK USA
(1) (2) (3) (4) (5) (6) (7) (8) (9) (10)
Tradet-1 0.072 0.074 0.117 0.211 -0.020 0.007 -0.870* -0.995* 0.306* 0.307**
(0.178) (0.188) (0.369) (0.391) (0.100) (0.099) (0.523) (0.530) (0.157) (0.118)
Exportt-1 0.007 0.007 -0.007 -0.009 0.027** 0.020 0.028 0.027 -0.002 -0.006
(0.009) (0.009) (0.010) (0.010) (0.012) (0.013) (0.018) (0.018) (0.008) (0.007)
EXEC 0.014 0.021 -0.013 -0.024 0.049 0.040 -0.033 -0.025 0.030 0.071
(0.060) (0.060) (0.064) (0.066) (0.077) (0.080) (0.076) (0.080) (0.078) (0.078)
EXEC*Tradet-1 -0.088 -0.122 -0.658*** -0.620*** -0.003 -0.002 0.608 0.593 -0.103* -0.067
(0.097) (0.093) (0.226) (0.235) (0.180) (0.177) (0.444) (0.443) (0.053) (0.042)
EXEC*Exportt-1 -0.000 -0.002 0.014 0.015 -0.009 -0.007 -0.013 -0.015* 0.003 0.003
(0.004) (0.003) (0.010) (0.010) (0.011) (0.010) (0.009) (0.009) (0.004) (0.004)
Year FE's N Y N Y N Y N Y N Y
Observations 2516 2516 2718 2718 2663 2663 2118 2118 2320 2320
R-squared 0.022 0.043 0.078 0.093 0.084 0.103 0.025 0.052 0.034 0.147
Number of recipients 103 103 105 105 104 104 92 92 97 97
Model F (p-value) 0.021 0.000 0.000 0.000 0.000 0.000 0.003 0.000 0.000 0.000
Joint F (p-value) 0.839 0.491 0.0145 0.0642 0.298 0.712 0.197 0.105 0.376 0.0531
NOTE. FE = fixed effects. All regressions are FE estimations. All columns include country fixed effects and donor and recipient demographic controls. Year
dummies are not shown. P-values are reported for the test of joint significance of bilateral Trade Share and Export Share variables, Elections dummy and their
interactions. Robust standard errors are in parentheses and clustered at recipients, *** p<0.01, ** p<0.05, * p<0.10.
34
Table 9
Pooled Election Year Differences in ODA Commitments by Political Competitiveness
1975-2008
Dependent variable is log ODA commitments
Year-to-Year Regime-Specific
(1) (2) (3) (4)
Politically Non-Competitive
Tradet-1 (
!
"1) 0.113 0.170* 0.127 0.165
(0.090) (0.100) (0.109) (0.113)
Exportt-1 (
!
" 2 ) -0.002 -0.003 0.002 -0.000
(0.004) (0.004) (0.006) (0.005)
EXECt (
!
" 3 ) 0.000 0.022 0.014 0.034
(0.062) (0.061) (0.066) (0.065)
EXECt*Tradet-1 (
!
" 4 ) -0.208 -0.268* -0.224* -0.328**
(0.127) (0.138) (0.126) (0.132)
EXECt*Exportt-1 (
!
" 5 ) 0.012** 0.010* 0.009 0.008
(0.006) (0.006) (0.006) (0.005)
Politically Competitive
PCOMPt-1 (
!
" 6 ) 0.106 0.227*** 0.094 0.214***
(0.073) (0.073) (0.077) (0.078)
EXECt*PCOMPt-1 (
!
" 7 ) -0.012 -0.025 -0.015 -0.026
(0.071) (0.070) (0.076) (0.074)
PCOMPt-1*Tradet-1 (
!
" 8 ) -0.223 -0.229 -0.245 -0.253
(0.135) (0.140) (0.162) (0.171)
EXECt*PCOMPt-1*Tradet-1 (
!
" 9 ) 0.180 0.254* 0.226* 0.347**
(0.130) (0.142) (0.130) (0.137)
PCOMPt-1*Exportt-1 (
!
"10) 0.012** 0.009* 0.014** 0.012*
(0.005) (0.005) (0.006) (0.006)
EXECt*PCOMPt-1*Exportt-1 (
!
"11) -0.011* -0.009 -0.010* -0.010
(0.006) (0.006) (0.006) (0.006)
Year FE's N Y N Y
Observations 12370 12370 12335 12335
R-squared 0.016 0.043 0.016 0.043
Number of donor-recipient pairs 501 501 501 501
Model F (p-value) 0.000 0.000 0.000 0.000
Joint F (p-value) 0.0140 0.00497 0.0647 0.00383
NOTE. FE = fixed effects. All regressions are FE estimations. All columns include country fixed effects
and donor and recipient demographic controls. Year dummies are not shown. P-values are reported for the
test of joint significance of bilateral Trade Share and Export Share variables, Elections and Political
Competitiveness dummies and their interactions. Robust standard errors are in parentheses and clustered at
donor-recipient pairs, *** p<0.01, ** p<0.05, * p<0.10.
35
Table 10
Summary of Election Year Differences in ODA Commitments
by Political Competitiveness Disaggregated by Donor
Regime Specific
Dependent variable is log ODA commitments
Pooled France Germany Japan UK USA
(1) (2) (3) (4) (5) (6)
EXECt (
!
" 3 ) (+) (-) (+/-) (+) (+) (-/+)
PCOMPt-1 (
!
" 6 ) (+)/*** (+) (+)* (+)*
/** (+)**
/* (-)
EXECt*PCOMPt-1 (
!
" 7 ) (-) (+) (-/+) (-) (-) (-)
Tradet-1 (
!
"1) (+) (+) (+) (+) (-) (+)***
EXECt*Tradet-1 (
!
" 4 ) (-)*/** (-) (-)*
/ (-) (+/-) (-)
/*
PCOMPt-1*Tradet-1 (
!
" 8 ) (-) (+) (+/-) (-)*** (-)**/* (-)***
EXECt*PCOMPt-1*Tradet-1 (
!
" 9 ) (+)*/** (-) (+) (+) (+)
/* (+)
/*
Exportt-1 (
!
" 2 ) (+/-) (+) (-) (+) (-) (-)*/**
EXECt*Exportt-1 (
!
" 5 ) (+) (+) (+) (+) (+/-) (+)**
PCOMPt-1*Exportt-1 (
!
"10) (+)**/* (-) (-) (+) (+)*** (+)**
EXECt*PCOMPt-1*Exportt-1 (
!
"11) (-)*/ (-) (+) (-) (-) (-)**
NOTE. The results in Column (1) above are a summary of the signs and significance of the Regime-
Specific pooled fixed effects regression in Columns (3) and (4) of Table 9, with the latter specification
including year fixed effects. The remaining columns present analogous results for the five bilateral donors
separately. The full set of regression results for these remaining columns can be found in Tables B1, B2,
B3, B4 and B5 in Appendix B. Asterisks (*) denote the significance of the coefficient signs at the standard
levels. Where signs on the coefficients or the level of significance vary in the two specifications, the
results are separated by a slash (/), where the element before the slash represents the result in the
specification without year fixed effects and the element after the slash denotes the result with fixed effects.
Robust standard errors in the original regressions are clustered at donor-recipient pairs for column (1) and
at recipients for columns (2) - (6), *** p<0.01, ** p<0.05, * p<0.10.
36
Table 11
Tests of Linear Combinations of Interactions by Donor
Regime Specific
France Germany Japan UK USA
Linear Combinations/ Regression (1) (2) (3) (4) (5)
EXEC/PCOMP
(1) EXEC + EXEC*PCOMP
!
" 3 + " 7( ) (+) (-) (+) (-) (+)
(2) PCOMP + EXEC*PCOMP
!
" 6 + " 7( ) (+) (+) (+) (+) (-)
Trade
(3) Trade + EXEC*Trade
!
"1+ " 4( ) (-) (-) (-) (-) (-)
(4) Trade + PCOMP*Trade
!
"1+ " 8( ) (+) (+) (-)*** (-)***/** (+)
(5) Trade + EXEC*Trade + PCOMP*Trade + EXEC*PCOMP*Trade
!
"1+ " 4 + " 8 + " 9( ) (+/-) (-) (-)* (-)**/* (+)
(6) EXEC*Trade + EXEC*PCOMP*Trade
!
" 4 + " 9( ) (-) (-) (+) (+)/* (-)
Export
(7) Export + EXEC*Export
!
" 2 + " 5( ) (+) (+) (+) (-) (+)
(8) Export + PCOMP*Export
!
" 2 + "10( ) (+) (-) (+)**/ (+)*** (+)
(9) Export + EXEC*Export + PCOMP*Export + EXEC*PCOMP*Export
!
" 2 + " 5 + "10 + "11( ) (-) (+) (+) (+)/** (+)
/*
(10) EXEC*Export + EXEC*PCOMP*Export
!
" 5 + "11( ) (-) (+) (-)*/ (-) (-)
NOTE. The tests of linear combinations correspond to Columns (3) and (4) of the regressions presented in Tables B1 through B5 in Appendix B and
summarized above in Table 10. The relevant regressions use Regime-Specific measures of Trade and Export for the five bilateral donors and the specification in
the two columns differ in that Column (4) uses year fixed effects. Asterisks (*) denote the significance of the signs on the coefficient of the linear combinations
at the standard levels. Where signs on the coefficients or the level of significance vary in the two specifications, the results are separated by a slash (/), where the
element before the slash represents the result in the specification without year fixed effects and the element after the slash denotes the result with fixed effects.
*** p<0.01, ** p<0.05, * p<0.10.
37
Appendix B Regressions Summarized in Tables 10 and 11
Table B1
Election Year Differences in ODA Commitments by Political Competitiveness
1975-2008
France
Dependent variable is log ODA commitments
Year-to-Year Regime-Specific
(1) (2) (3) (4)
Politically Non-Competitive
Tradet-1 -0.014 0.015 0.042 0.047
(0.142) (0.155) (0.195) (0.206)
Exportt-1 0.002 0.003 0.009 0.009
(0.006) (0.006) (0.009) (0.008)
EXECt -0.065 -0.040 -0.089 -0.058
(0.112) (0.112) (0.117) (0.116)
EXECt*Tradet-1 0.004 -0.052 -0.068 -0.109
(0.094) (0.097) (0.089) (0.103)
EXECt*Exportt-1 0.001 -0.001 0.005 0.002
(0.006) (0.007) (0.005) (0.006)
Politically Competitive
PCOMPt-1 0.174 0.199 0.147 0.173
(0.126) (0.123) (0.129) (0.127)
EXECt*PCOMPt-1 0.081 0.058 0.144 0.113
(0.141) (0.139) (0.148) (0.146)
PCOMPt-1*Tradet-1 0.152 0.125 0.215 0.179
(0.279) (0.279) (0.309) (0.309)
EXECt*PCOMPt-1*Tradet-1 -0.067 0.014 -0.187 -0.126
(0.334) (0.360) (0.358) (0.374)
PCOMPt-1*Exportt-1 -0.012** -0.012* -0.006 -0.006
(0.006) (0.006) (0.006) (0.007)
EXECt*PCOMPt-1*Exportt-1 0.003 0.004 -0.006 -0.004
(0.008) (0.008) (0.008) (0.008)
Year FE's N Y N Y
Observations 2523 2523 2516 2516
R-squared 0.024 0.045 0.025 0.047
Number of recipients 103 103 103 103
Model F (p-value) 0.033 0.000 0.001 0.000
Joint F (p-value) 0.618 0.125 0.400 0.0959
NOTE. FE = fixed effects. All regressions are FE estimations. All columns include country fixed effects and donor
and recipient demographic controls. Year dummies are not shown. P-values are reported for the test of joint
significance of bilateral Trade Share and Export Share variables, Elections and Political Competitiveness dummies
and their interactions. Robust standard errors are in parentheses and clustered at recipients, *** p<0.01, ** p<0.05, *
p<0.10.
38
Table B2
Election Year Differences in ODA Commitments by Political Competitiveness
1975-2008
Germany
Dependent variable is log ODA commitments
Year-to-Year Regime-Specific
(1) (2) (3) (4)
Politically Non-Competitive
Tradet-1 0.138 0.239 0.119 0.222
(0.381) (0.396) (0.395) (0.412)
Exportt-1 -0.003 -0.005 -0.005 -0.006
(0.009) (0.009) (0.013) (0.013)
EXECt -0.066 -0.109 0.014 -0.036
(0.121) (0.120) (0.148) (0.149)
EXECt*Tradet-1 -0.930** -0.857* -0.796* -0.745
(0.432) (0.453) (0.447) (0.458)
EXECt*Exportt-1 0.025 0.026* 0.009 0.011
(0.016) (0.016) (0.023) (0.022)
Politically Competitive
PCOMPt-1 0.209* 0.220* 0.201* 0.221*
(0.113) (0.117) (0.116) (0.120)
EXECt*PCOMPt-1 0.070 0.110 -0.031 0.016
(0.137) (0.136) (0.164) (0.164)
PCOMPt-1*Tradet-1 0.019 -0.043 0.027 -0.048
(0.480) (0.495) (0.560) (0.565)
EXECt*PCOMPt-1*Tradet-1 0.432 0.421 0.231 0.220
(0.650) (0.685) (0.706) (0.722)
PCOMPt-1*Exportt-1 -0.005 -0.007 -0.003 -0.006
(0.012) (0.013) (0.016) (0.017)
EXECt*PCOMPt-1*Exportt-1 -0.017 -0.015 0.007 0.007
(0.024) (0.023) (0.032) (0.031)
Year FE's N Y N Y
Observations 2725 2725 2718 2718
R-squared 0.082 0.098 0.082 0.097
Number of recipients 105 105 105 105
Model F (p-value) 0.000 0.000 0.000 0.000
Joint F (p-value) 0.124 0.164 0.0251 0.0708
NOTE. FE = fixed effects. All regressions are FE estimations. All columns include country fixed effects and donor
and recipient demographic controls. Year dummies are not shown. P-values are reported for the test of joint
significance of bilateral Trade Share and Export Share variables, Elections and Political Competitiveness dummies
and their interactions. Robust standard errors are in parentheses and clustered at recipients, *** p<0.01, ** p<0.05, *
p<0.10.
39
Table B3
Election Year Differences in ODA Commitments by Political Competitiveness
1975-2008
Japan
Dependent variable is log ODA commitments
Year-to-Year Regime-Specific
VARIABLES (1) (2) (3) (4)
Politically Non-Competitive
Tradet-1 0.034 0.082 0.021 0.052
(0.092) (0.093) (0.102) (0.101)
Exportt-1 0.006 0.004 0.019 0.013
(0.007) (0.007) (0.012) (0.012)
EXECt 0.092 0.116 0.149 0.179
(0.164) (0.163) (0.173) (0.174)
EXECt*Tradet-1 0.777 0.798 -0.101 -0.232
(1.134) (1.259) (0.510) (0.545)
EXECt*Exportt-1 0.012 0.010 0.007 0.007
(0.020) (0.020) (0.017) (0.016)
Politically Competitive
PCOMPt-1 0.329* 0.433** 0.350* 0.452**
(0.167) (0.168) (0.177) (0.177)
EXECt*PCOMPt-1 -0.093 -0.138 -0.125 -0.174
(0.189) (0.187) (0.205) (0.204)
PCOMPt-1*Tradet-1 -0.534*** -0.537*** -0.698*** -0.700***
(0.194) (0.183) (0.175) (0.175)
EXECt*PCOMPt-1*Tradet-1 -0.730 -0.701 0.245 0.386
(1.148) (1.257) (0.569) (0.586)
PCOMPt-1*Exportt-1 0.019 0.012 0.018 0.012
(0.012) (0.012) (0.015) (0.016)
EXECt*PCOMPt-1*Exportt-1 -0.020 -0.016 -0.032 -0.028
(0.026) (0.026) (0.021) (0.020)
Year FE's N Y N Y
Observations 2670 2670 2663 2663
R-squared 0.095 0.116 0.097 0.118
Number of recipients 104 104 104 104
Model F (p-value) 0.000 0.000 0.000 0.000
Joint F (p-value) 0.00590 0.0338 0.000557 0.00457
NOTE. FE = fixed effects. All regressions are FE estimations. All columns include country fixed effects and donor
and recipient demographic controls. Year dummies are not shown. P-values are reported for the test of joint
significance of bilateral Trade Share and Export Share variables, Elections and Political Competitiveness dummies
and their interactions. Robust standard errors are in parentheses and clustered at recipients, *** p<0.01, ** p<0.05, *
p<0.10.
40
Table B4
Election Year Differences in ODA Commitments by Political Competitiveness
1975-2008
UK
Dependent variable is log ODA commitments
Year-to-Year Regime-Specific
VARIABLES (1) (2) (3) (4)
Politically Non-Competitive
Tradet-1 0.095 0.031 -0.140 -0.256
(0.527) (0.584) (0.502) (0.527)
Exportt-1 -0.017 -0.020* -0.003 -0.004
(0.011) (0.012) (0.009) (0.009)
EXECt 0.041 0.040 0.045 0.043
(0.128) (0.129) (0.131) (0.133)
EXECt*Tradet-1 -0.046 -0.203 0.095 -0.003
(0.217) (0.240) (0.187) (0.216)
EXECt*Exportt-1 0.002 -0.004 0.001 -0.002
(0.013) (0.012) (0.006) (0.006)
Politically Competitive
PCOMPt-1 0.387*** 0.372** 0.311** 0.296*
(0.147) (0.158) (0.150) (0.159)
EXECt*PCOMPt-1 -0.117 -0.116 -0.124 -0.122
(0.157) (0.161) (0.160) (0.163)
PCOMPt-1*Tradet-1 -2.029** -1.858* -2.228** -2.053*
(0.936) (1.057) (1.069) (1.165)
EXECt*PCOMPt-1*Tradet-1 1.094 1.458* 0.940 1.203*
(0.846) (0.872) (0.608) (0.609)
PCOMPt-1*Exportt-1 0.045*** 0.046*** 0.053*** 0.053***
(0.016) (0.017) (0.014) (0.014)
EXECt*PCOMPt-1*Exportt-1 -0.023 -0.016 -0.016 -0.011
(0.023) (0.022) (0.021) (0.022)
Year FE's N Y N Y
Observations 2125 2125 2118 2118
R-squared 0.041 0.067 0.058 0.083
Number of recipients 92 92 92 92
Model F (p-value) 0.000 0.000 0.000 0.000
Joint F (p-value) 0.000381 0.00104 8.17e-06 3.23e-05
NOTE. FE = fixed effects. All regressions are FE estimations. All columns include country fixed effects and donor
and recipient demographic controls. Year dummies are not shown. P-values are reported for the test of joint
significance of bilateral Trade Share and Export Share variables, Elections and Political Competitiveness dummies
and their interactions. Robust standard errors are in parentheses and clustered at recipients, *** p<0.01, ** p<0.05, *
p<0.10.
41
Table B5
Election Year Differences in ODA Commitments by Political Competitiveness
1975-2008
USA
Dependent variable is log ODA commitments
Year-to-Year Regime-Specific
VARIABLES (1) (2) (3) (4)
Politically Non-Competitive
Tradet-1 1.041*** 0.888*** 0.959*** 0.817***
(0.088) (0.091) (0.090) (0.091)
Exportt-1 -0.016** -0.018*** -0.017* -0.020**
(0.007) (0.006) (0.010) (0.009)
EXECt 0.031 0.120 -0.001 0.088
(0.127) (0.114) (0.140) (0.128)
EXECt*Tradet-1 -3.924 -3.795 -3.326 -3.368*
(2.704) (2.375) (2.014) (1.844)
EXECt*Exportt-1 0.028** 0.022* 0.029** 0.024**
(0.012) (0.013) (0.011) (0.011)
Politically Competitive
PCOMPt-1 -0.187 -0.020 -0.219 -0.039
(0.230) (0.233) (0.250) (0.254)
EXECt*PCOMPt-1 -0.011 -0.063 0.036 -0.018
(0.155) (0.145) (0.167) (0.157)
PCOMPt-1*Tradet-1 -1.001*** -0.789*** -0.894*** -0.693***
(0.115) (0.118) (0.129) (0.129)
EXECt*PCOMPt-1*Tradet-1 3.872 3.762 3.298 3.362*
(2.706) (2.377) (2.019) (1.847)
PCOMPt-1*Exportt-1 0.025*** 0.024*** 0.027** 0.024**
(0.008) (0.008) (0.010) (0.010)
EXECt*PCOMPt-1*Exportt-1 -0.028** -0.021* -0.030** -0.024**
(0.012) (0.013) (0.012) (0.011)
Year FE's N Y N Y
Observations 2327 2327 2320 2320
R-squared 0.058 0.164 0.054 0.163
Number of recipients 97 97 97 97
Model F (p-value) 0.000 0.000 0.000 0.000
Joint F (p-value) 0 0 0 5.85e-11
NOTE. FE = fixed effects. All regressions are FE estimations. All columns include country fixed effects and donor
and recipient demographic controls. Year dummies are not shown. P-values are reported for the test of joint
significance of bilateral Trade Share and Export Share variables, Elections and Political Competitiveness dummies
and their interactions. Robust standard errors are in parentheses and clustered at recipients, *** p<0.01, ** p<0.05, *
p<0.10.