Risk of Manic Switch Associated With Antidepressant Therapy in Pediatric Bipolar Depression...
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Risk of Manic Switch Associated with AntidepressantTherapy in Pediatric Bipolar Depression
Debajyoti Bhowmik, PhD,1,2 Rajender R. Aparasu, MPharm, PhD, FAPhA,1 Suja S. Rajan, MS, PhD, MPA,3
Jeffrey T. Sherer, PharmD, MPH,1 Melissa Ochoa-Perez, MD,4 and Hua Chen, MD, PhD1
Abstract
Objective: The purpose of this study was to assess the risk of manic switch associated with antidepressants in Medicaid-enrolled pediatric patients with bipolar depression.
Methods: This retrospective cohort study involved 20032007 Medicaid Analytic eXtract (MAX) data from four geo-graphically diverse states. The study sample included children and adolescents (ages 618 years) who had received a
diagnosis of bipolar disorder on two or more separate occasions or during a hospital discharge, followed by a diagnosis of
depression. According to the pharmacotherapy received by these patients in the 30 days around the index bipolar depression
diagnosis, patients were categorized into five mutually exclusive groups. Manic switch was defined as having received a
diagnosis of mania within 6 weeks after the initiation of bipolar depression treatment. Relative risks of manic switch between
antidepressant monotherapy/polytherapy and their alternatives were assessed using Cox proportional hazards model. The
robustness of the conventional Cox proportional hazards model toward possible bias caused by unobserved confounders was
tested using instrumental variable analysis, and the uncertainty regarding manic switch definition was tested by altering the
duration of follow-up.
Results: After applying all the selection criteria, 179 antidepressant monotherapy, 1047 second-generation antipsychotic(SGA) monotherapy, 570 mood stabilizer monotherapy, 445 antidepressant polytherapy, and 1906 SGAmood stabilizer
polytherapy users were identified. In Cox proportional hazard analyses, both antidepressant monotherapy and polytherapy
exhibited higher risk of manic switch than their alternatives (antidepressant monotherapy vs. SGA monotherapy, hazard ratio
[HR] = 2.87 [95% CI: 1.107.49]; antidepressant monotherapy vs. mood stabilizer monotherapy, HR = 1.41 [95% CI: 0.523.80); antidepressant polytherapy vs. SGA-mood stabilizer polytherapy, HR = 1.61 [95% CI: 0.902.89]). However, only thecomparison between antidepressant monotherapy and SGA monotherapy was statistically significant. The instrumental
variable analysis did not detect endogeneity of the treatment variables. Extending the follow-up period from 6 weeks to 8 and
12 weeks generated findings consistent with the main analysis.
Conclusions: Study findings indicated a higher risk of manic switch associated with antidepressant monotherapy than withSGA monotherapy in pediatric patients with bipolar depression. The finding supported the clinical practice of cautious
prescribing of antidepressants for brief periods.
Introduction
Bipolar disorder is a form of mood disorder characterizedby the presence of episodes of highly elevated mood (manic)and episodes of depression. The lifetime prevalence of the de-
pressive phase among bipolar disorder patients is threefold higher
than that of the mania phase (Post et al. 2003). Among the phases of
bipolar disorder, untreated bipolar depression, particularly in
children and adolescents, is associated with the highest risk of
suicidality (Tondo et al. 1998), substance abuse, functional dis-
ability, and poor academic and social performance (Angst et al.
2002; Frye et al. 2006; Thase 2006; Dutta et al. 2007; Huxley and
Baldessarini 2007; Tondo et al. 2007; Baldessarini et al. 2008).
Until 2002, antidepressant monotherapy had been recommended
as the first-line treatment for bipolar depression in all treatment
guidelines for adults (Baldessarini et al. 2007; Amit and Weizman
2012). That year, the American Psychiatric Association (APA)
treatment guidelines relegated antidepressants to second-line use
after initial treatment with mood stabilizer monotherapy (Hirsch-
feld et al. 2002). However, there has been debate over whether
1Department of Pharmaceutical Health Outcomes and Policy, College of Pharmacy, University of Houston, Houston, Texas.2Global Health Economics, Amgen Inc., Thousand Oaks, California.3Division of Management, Policy and Community Health, School of Public Health, The University of Texas Health Science Center, Houston, Texas.4Department of Psychiatry, Legacy Community Health Services, Houston, Texas.
JOURNAL OF CHILD AND ADOLESCENT PSYCHOPHARMACOLOGYVolume 24, Number 10, 2014 Mary Ann Liebert, Inc.Pp. 551561DOI: 10.1089/cap.2014.0028
551
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antidepressants are safe and effective medications for the condition,
both before and after the APA revision. Multiple observational
studies including patients self-reports and naturalistic studies re-
ported a higher risk of manic switch associated with the use of
antidepressants in adults with bipolar depression (Peet 1994; Alt-
shuler et al. 1995; Boerlin et al. 1998; Henry et al. 2001; Ghaemi
et al. 2003; Truman et al. 2007). However, most of the clinical trials
included in the review by Licht et al. (2008) and in the meta-
analysis by Gijsman et al. (2004) did not find statistically signifi-
cant differences between antidepressants and placebo regarding the
risk of manic switch.
Critical evaluation of these clinical trials suggested that it is
difficult to make a confirmatory conclusion based on available
evidence, because of the presence of biases in the existing trials
(Licht et al. 2008). For example, in some of the randomized con-
trolled trials (RCTs) that compared the risk of manic switch be-
tween antidepressants and placebo, 75% of the patients were
concomitantly treated with mood stabilizers or second-generation
antipsychotics (SGAs). Also, these trials captured manic switch
during various follow-up times, and did not report whether the
switch occurred during acute treatment for depression or after re-
mission, thereby drawing inconclusive evidence for manic switch
risk with antidepressants (Licht et al. 2008).
Bipolar disorder with childhood onset seems to be more severe
than the form that first appears in adults (Perlis et al. 2004; Birmaher
et al. 2006). Although there are no empirical data available to clarify
the association between antidepressant monotherapy and the risk of
manic switch in this subgroup, some indirect evidence suggests that
children and adolescents with bipolar disorder may have symptoms
more often and switch moods more frequently than adults with the
illness. In a recent study conducted among a cohort of youth (920
years) with depressive and anxiety disorders, and with at least one
parent with bipolar I disorder, 21% had been treated with anti-
depressants. Among these antidepressant recipients, 57% had had an
adverse reaction in the form of manic symptoms (irritability, ag-
gression, impulsivity, or hyperactivity), leading to antidepressant
discontinuation (Strawn et al. 2014). Therefore, the existing pedi-
atric guidelines for bipolar disorder tend to be more conservative in
recommending the use of antidepressants. Antidepressant mono-
therapy was never recommended, and the use of antidepressants as
an adjunct treatment was mentioned as may not be necessary unless
the depressed phase persists or becomes severe (McClellan et al.
1997) and caution must be taken because antidepressants may
destabilize the patients mood or incite a manic episode (McClellan
et al. 2007). However, our previous research using Medicaid data
revealed that antidepressants were used in nearly half (48.17%) of
children and adolescents with bipolar depression, of whom 42.40%
received it as an adjunct treatment and 5.77% received is as a
monotherapy (Bhowmik et al. 2013).
Almost all existing clinical trials assessing manic switch asso-
ciated with the use of antidepressants compared them to placebo
(Mendlewicz and Youdim 1980; Himmelhoch et al. 1982; Cohn
et al. 1989; Nemeroff et al. 2001; Tohen et al. 2003). However, in
practice, the more clinically relevant issue is the risk from antide-
pressants versus their alternatives. Head-to-head comparison data
between antidepressant monotherapy and SGA/mood stabilizer
monotherapy, or between antidepressant polytherapy and SGA/
mood stabilizer polytherapy, are needed. Therefore, the objectives
of this study were to evaluate the comparative risk of manic switch
associated with 1) antidepressant monotherapy versus SGA
monotherapy, 2) antidepressant monotherapy versus mood stabi-
lizer monotherapy, and 3) antidepressant polytherapy (with SGA or
mood stabilizer) versus SGA-mood stabilizer polytherapy in
Medicaid-enrolled children and adolescents with bipolar depres-
sion. We hypothesized that an antidepressant, when used alone or in
combination with a mood stabilizer/SGA in children with bipolar
depression, was associated with increased risk of manic switch
compared with corresponding SGA and mood stabilizer mono-
therapies or combination.
Methods
Data source
In this retrospective cohort study, 20032007 Medicaid Analytic
eXtract (MAX) files from the Center for Medicare and Medicaid
Services (CMS) were used to achieve the study objectives. The
MAX is a set of person-level claims data files containing infor-
mation on Medicaid eligibility, demographics, service utilization,
and payments. We used data from four geographically diverse
states with large Medicaid enrolments of children and adolescents
(CA, TX, IL, and NY).
Pharmacotherapy for bipolar depression
The pharmacotherapies for bipolar depression assessed in this
study were mood stabilizers (lithium, sodium divalproex/valproate,
oxcarbazepine, topiramate, lamotrigine, and gabapentin); SGA
(risperidone, aripiprazole, olanzapine, quetiapine, clozapine, and
ziprasidone); newer antidepressants (serotonin reuptake inhibitor
[SSRI] antidepressants and others, citalopram, escitalopram, flu-
oxetine, fluvoxamine, paroxetine, sertraline, venlafaxine, and bu-
propion); and other antidepressants (amitriptyline, clomipramine,
desipramine, doxepin, imipramine, nortriptyline, mirtazapine, ne-
fazodone, and trazodone) (Bhowmik et al. 2013).
Study population
The study design and cohort identification process are presented
in Figure 1. Children and adolescents with bipolar depression were
identified based on the following algorithm (Bhowmik et al. 2013):
1) 618 years of age (children and adolescents), 2) having received
a minimum of two diagnoses of bipolar disorder other than bipolar
depression (International Classification of Diseases, 9th version,
Clinical Modification [ICD-9-CM]: 296.0, 296.1, 296.4-296.8,
301.11, 301.13) on different service dates, or only one diagnosis of
bipolar disorder that came from hospital discharge, followed by a
diagnosis of depression (ICD-9-CM: 296.5, 296.2, 296.3) (Busch
et al. 2008) any time between January 2003 and December 2007;
and 3) having received antidepressants, SGA, or mood stabilizers
within 30 days of the depression diagnosis. The date on which the
first prescription of these medications was filled was defined as the
index date.
Exclusion criteria
Patients who received diagnoses of schizophrenia (ICD-9-CM:
295.0-295.9) or epilepsy (ICD-9-CM: 345.xx) were excluded from
the cohort, to increase the likelihood that the prescriptions were
used for the treatment of bipolar disorder. Patients without con-
tinuous Medicaid eligibility 2 months prior to and 3 months after
the index date were also excluded. Finally, for identification of new
users of antidepressants, patients who had received antidepressant
prescriptions during the 2 month pre-index period were excluded.
The bipolar depression patients identified were then divided
into five mutually exclusive groups based on their medication
552 BHOWMIK ET AL.
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use during 30 days around the index bipolar depression diag-
nosis: 1) Antidepressant monotherapy, 2) SGA monotherapy,
3) mood stabilizer monotherapy, 4) antidepressantSGA or
antidepressantmood stabilizer polytherapy, and 5) SGAmood
stabilizer polytherapy. Monotherapy was defined as receiving
medications from a single therapeutic class only, whereas
polytherapy was defined as receiving medications from differ-
ent therapeutic classes within 30 days of the depression di-
agnosis and with a minimum of 14 day overlap between the
prescriptions.
Manic switch
Manic switch events were identified from the combined inpa-
tient and other therapy MAX files, using the ICD-9-CM codes of
mania (296.0, 296.1, 296.4, 296.81) during the 6 week follow-up
period after the index date. The follow-up window was restricted to
6 weeks to differentiate manic events as being treatment emergent
rather than the natural progression of bipolar disorder itself (Sal-
vadore et al. 2010).
Statistical analyses
Descriptive analysis was conducted to describe the demo-
graphics, treatment utilization, comedications, and comorbidities
during the 2 month pre-index period for the monotherapy and
polytherapy users, respectively. Time to manic switch was ana-
lyzed using a multivariable Cox proportional hazards regression
model to assess the risk of manic switch associated with bipolar
depression treatment. The analyses evaluated antidepressant
monotherapy versus mood stabilizer or SGA monotherapy and
antidepressant polytherapy versus SGAmood stabilizer poly-
therapy. KaplanMeier plot, log-minus-log survival plot, and
Schoenfeld residual test were performed to test the proportionality
of hazard assumption. Patients were censored in the model upon: 1)
Discontinuation of the index treatment regimen, 2) augmentation
with a newer medication other than the index regimen, or 3) end of
follow- up. SAS 9.3 was used for the entire analyses and p < 0.05was considered to be statistically significant.
Covariates included in the Cox model were patient demo-
graphics, comedications, and comorbidities that were measured at 2
Excluded Patients without continuous eligibility 2 months
before and 3 months after the index pharmacotherapy for bipolar depression treatment = 589
Excluded patients with antidepressant use during the 2
months pre-index period = 2,051
Patients filled an antidepressant, an atypical antipsychotic or a mood
stabilizer during 30 days before or 30 days after the bipolar depression
diagnosis = 8,397
Excluded patients having diagnoses of epilepsy or schizophrenia = 8,731
Medicaid enrolees 6-18 years of age with any mental disorder diagnosis or
received any psychotropic drug = 4,216,094
Cohort : To observe the short term manic switch associated with
antidepressant exposure = 4,147
Follow-up = 6 weeks
Monotherapy cohort = 1,796
Polytherapy cohort = 2,351
Antidepressant monotherapy =
179
Atypical antipsychotic monotherapy
= 1,047
Antidepressant polytherapy =
445
Atypical antipsychotic-
mood stabilizer
polytherapy = 1,906
Mood stabilizer
monotherapy = 570
Excluded patients for computing physician prescribing preference =
4,250
Patients with two distinctive bipolar disorder diagnoses or one diagnosis
from hospital discharge followed by a depression diagnosis at any time
during Jan2003-Dec2007 = 14,009
FIG. 1. Consort diagram.
ANTIDEPRESSANTS ASSOCIATED WITH MANIC SWITCH IN CHILDREN 553
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months pre-index date. Comorbidities included previous manic
episodes identified by diagnosis codes of mania, substance abuse
disorder (SUD), attention-deficit/hyperactivity disorder (ADHD),
oppositional defiant disorder (ODD), anxiety, adjustment disorder,
and psychotic disorder at baseline. Comedications included stim-
ulants, sedatives, hypnotics, anticholinergics, SGAs, or mood sta-
bilizers at baseline. Uses of psychotherapy and hospital admissions
at baseline were identified as measures of disease severity. Patient
demographic characteristics included were age (categorized as
children if
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as recipients of antidepressant monotherapy (n = 179), SGAmonotherapy (n= 1047), mood stabilizer monotherapy (n = 570),antidepressantmood stabilizer or antidepressantSGA polyther-
apy (n = 445), or SGAmood stabilizer polytherapy (n= 1906).
Descriptive statistics
As presented in Tables 1 and 2, antidepressant (both mono-
therapy and polytherapy) recipients were older, more likely to be
female, less likely to be foster children, and less likely to have
comorbid ADHD or to receive stimulants than SGA and mood
stabilizer recipients. During the 6 week follow-up period, the
highest incidence of manic switch was observed in children and
adolescents receiving SGAmood stabilizer polytherapy (n = 218,11.44%), followed by mood stabilizer monotherapy (n = 62,10.88%), antidepressant monotherapy (n = 17, 9.50%), SGAmonotherapy (n= 95, 9.07%) and antidepressant polytherapy(n = 136, 8.09%). Using antidepressant monotherapy as the refer-ence, log rank tests found that there were no statistically significant
differences in the risk of manic switch between antidepressant
monotherapy recipients and the recipients of all other regimens.
Multivariable Cox proportional hazards regressionanalysis
Tables 35 present the findings of three traditional Cox pro-
portional hazard analysis models that compared the risk of manic
switch between antidepressant monotherapy and SGA mono-
therapy, antidepressant monotherapy and mood stabilizer mono-
therapy, and antidepressant polytherapy and SGAmood stabilizer
polytherapy after controlling for all observable confounders. An-
tidepressant monotherapy was associated with a higher risk
of manic switch than SGA monotherapy (HR = 2.87 [95% CI:1.107.49]). However, similar results were not found when anti-
depressant monotherapy was compared with mood stabilizer
monotherapy (HR = 1.41 [95% CI: 0.523.80]), and when antide-pressant polytherapy was compared with SGAmood stabilizer
polytherapy (HR = 1.61 [95% CI: 0.902.89]).
Table 1. Descriptive Results for the Monotherapy Cohort (n= 1796)
Antidepressantmonotherapy (n = 179)
SGA monotherapy(n = 1047)
Mood stabilizermonotherapy (n= 570)
Covariates n (%) or Mean ( SD) n (%) or Mean ( SD) n (%) or Mean ( SD) p value
DemographicsAge category
Children (613 years) 36 (20.45) 437 (42.55) 177 (31.83) < 0.0001Adolescents (1418 years) 140 (79.55) 590 (57.45) 379 (68.17)
RaceWhite 89 (50.28) 461 (44.58) 260 (46.43) 0.0630Black 32 (18.08) 291 (28.14) 157 (28.04)
Gender (Male) 71 (40.11) 650 (62.86) 321 (57.32) < 0.0001State
TX 76 (42.94) 320 (30.95) 164 (29.29) 0.0025CA 36 (20.34) 206 (19.92) 124 (22.14)IL 51 (28.21) 340 (32.88) 201 (35.89)NY 14 (7.91) 168 (16.25) 71 (12.68)
Number of physicians in ZIP codes 23 ( 23) 31 ( 29) 29 ( 28) 0.0007Proxy measurements of severity
Duration of disease 328 ( 364) 334 ( 372) 295 ( 338) 0.1012Prior hospitalization 41 (22.91) 211 (20.15) 101 (17.72) 0.2574
Medicaid eligibility groupsFoster care 32 (17.88) 322 (30.75) 160 (28.07) 0.0019TANF 14 (7.82) 80 (7.64) 48 (8.42) 0.8562
ComorbiditySubstance abuse disorder 15 (8.38) 73 (6.97) 44 (7.72) 0.7363ADHD 35 (19.55) 339 (32.38) 150 (26.32) 0.0004Suicidality 9 (5.03) 22 (2.10) 9 (1.58) 0.0221Oppositional defiant disorder 27 (15.08) 262 (25.02) 123 (21.58) 0.0090Anxiety 26 (14.53) 95 (9.07) 61 (10.70) 0.0712Adjustment disorder 16 (8.94) 123 (11.75) 65 (11.40) 0.5488Psychotic disorder 5 (2.79) 81 (7.74) 23 (4.04) 0.0018Mania 23 (12.85) 134 (12.80) 87 (15.26) 0.3676
ComedicationStimulant 29 (16.20) 209 (19.96) 105 (18.42) 0.4389Sedative 48 (26.82) 177 (16.91) 102 (17.89) 0.0063Hypnotic 4 (2.23) 50 (4.78) 16 (2.81) 0.0711Anticholinergic 4 (2.23) 71 (6.78) 22 (3.86) 0.0065Psychotherapy 102 (56.98) 543 (51.86) 309 (54.21) 0.3661SGA 12 (6.70) 539 (51.48) 38 (6.67) < 0.0001Mood stabilizer 9 (5.03) 61 (5.83) 276 (48.42) < 0.0001
SGA, second-generation antipsychotic; ADHD, attention-deficit/hyperactivity disorder; TANF, Temporary Assistance for Needy Families.
ANTIDEPRESSANTS ASSOCIATED WITH MANIC SWITCH IN CHILDREN 555
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Among all three models, a prior manic episode was a very strong
predictor of short-term manic switch with an HR of 14.00 (95% CI:
8.9921.78) for the comparison between antidepressant mono-
therapy and SGA monotherapy, 17.80 (95% CI: 10.2930.81) for
the comparison between antidepressant monotherapy and mood
stabilizer monotherapy, and 10.96 (95% CI: 8.3614.37) when
antidepressant polytherapy was compared with SGAmood stabi-
lizer polytherapy.
IV analysis
Table 6 presents the statistical validation of instrumental vari-
ables. The F statistic for all three comparisons ranged from 149 to
285, and the partial R2 ranged from 0.27 to 0.40 which were well
above the widely used rule of thumb (i.e., 10 for F statistic) indi-
cated by Staiger and Stock (1997). These measures implied that the
instrumental variables selected for the study were strong predictors
of treatment selection.
Tables 35 present the findings of IV analysis using 2SRI
models. It was found that the residuals (r) generated from the first
stage regressions were not statistically significant in the second
stage model in all three comparisons, which might imply exo-
geneity of the treatment selection for bipolar depression.
Sensitivity analysis on duration of follow-up
As presented in Tables 35, the associations between the treat-
ment regimens and the risk of short-term manic switch remained
consistent when the follow-up period was extended from 6 weeks to
8 and 12 weeks.
Discussion
Consistent with existing adult data (Yatham et al. 2005; Bond
et al. 2008; Frye et al. 2009; Perlis et al. 2010), previous manic
episode was identified in our study as the most important predictor
(HR ranged from 11 to 18 for the three comparisons) for short-term
Table 2. Descriptive Results for the Polytherapy Cohort (n = 2351)
Antidepressant polytherapy (n = 445) SGA/Mood stabilizer polytherapy (n = 1906)Covariates n (%) or Mean ( SD) n (%) or Mean ( SD) p value
DemographicsAge category
Children 156 (36.03) 808 (43.49) 0.0046Adolescents 277 (63.97) 1050 (56.51)
RaceWhite 209 (47.83) 885 (47.33) 0.0061Black 86 (19.68) 487 (26.04)
Gender: Male 236 (54.00) 1268 (67.81) < 0.0001State
TX 228 (52.17) 747 (39.95) < 0.0001CA 75 (17.16) 336 (17.97)IL 112 (25.63) 485 (25.94)NY 22 (5.03) 302 (16.15)
Number of physicians in ZIP codes 26 ( 24) 33 ( 29) < 0.0001Proxy measurements of severity
Duration of disease 295 ( 369) 392 ( 377) < 0.0001Prior hospitalization 139 (31.24) 322 (16.89) < 0.0001
Medicaid eligibility groupsFoster care 83 (18.65) 651 (34.16) < 0.0001TANF 49 (11.01) 90 (4.72) < 0.0001
ComorbiditySubstance abuse disorder 28 (6.29) 97 (5.09) 0.3085ADHD 128 (28.76) 602 (31.58) 0.2470Suicidality 10 (2.25) 31 (1.63) 0.3677Oppositional defiant disorder 87 (19.55) 487 (25.55) 0.0080Anxiety 65 (14.61) 145 (7.61) < 0.0001Adjustment disorder 58 (13.03) 238 (12.49) 0.7542Psychotic disorder 32 (7.19) 149 (7.82) 0.6554Mania 56 (12.58) 296 (15.53) 0.1169
ComedicationStimulant 61 (13.71) 442 (23.19) < 0.0001Sedative 109 (24.49) 440 (23.08) 0.5269Hypnotic 20 (4.49) 93 (4.88) 0.7325Anticholinergic 27 (6.07) 175 (9.18) 0.0348Psychotherapy 286 (64.27) 1071 (56.19) 0.0019SGA 151 (33.93) 1375 (72.14) < 0.0001Mood stabilizer 67 (15.06) 1323 (69.41) < 0.0001
SGA, second-generation antipsychotic; ADHD, attention-deficit/hyperactivity disorder; TANF, Temporary Assistance for Needy Families.
556 BHOWMIK ET AL.
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manic switch in children and adolescents with bipolar depression.
The finding is consistent with the general belief that polarity switch
may be a part of the natural course of bipolar disorder itself. Irre-
spective of antidepressant treatment status, subjects who had had a
manic episode prior to the treatment initiation were more likely to
transition to a manic phase than were those without the previous
episode. Consequently, previous manic history should be an im-
portant consideration in treatment decisions.
After adjusting for previous manic episode and other covariates,
the Cox proportional hazard analysis suggested that antidepressant
monotherapy was associated with increased risk of manic switch
compared with SGA monotherapy (HR = 2.63). The higher risk ofmanic switch associated with antidepressants versus SGA could be
explained by the psychotropics mechanism of action, as described
in previous literature. Previous animal and genetic studies have
explored the potential role of many neurotransmitters in manic
switch, including serotonin, noradrenergic, dopamine, and cate-
cholaminergic activity (Salvadore et al. 2010). The mechanism that
helps to explain the different effects of antidepressants and SGA on
manic switch is the effect of these medications on regulating syn-
aptic plasticity and a-amino-3-hydroxy-5-methyl-4-isoxazole pro-pionic acid (AMPA) receptor trafficking in the hippocampus region
of brain that is associated with SGA. The exposure to antidepres-
sants (such as imipramine) known for triggering manic switch has
been reported earlier to increase AMPA synaptic expression in the
hippocampus (Du et al. 2003; Gray et al. 2003). Other research
suggests that treatment of rodents with antipsychotics can reduce
the expression of some AMPA receptor subunit mRNA and protein
expression (Fitzgerald et al. 1995; Healy and Meador-Woodruff
1997; Fumagalli et al. 2008). Given the opposing effect of SGA and
antidepressant drugs on the AMPA GluR1 receptor, AMPA re-
ceptor trafficking has been strongly suggested to play a key role in
the mechanism of manic switching.
Existing research suggests that mood stabilizers such as lithium
and valproate have similar effects as SGA on reducing glutamate
AMPA receptor (GluR1) synaptic expression in the hippocampus
(Du et al. 2004). However, statistically significant differences in the
Table 3. Cox Proportional Hazards Regression AnalysisResults (Antidepressant Monotherapy vs.
Second-Generation Antipsychotic [SGA] Monotherapy)
Variables
Hazard ratio(95% CI) from
conventional Coxproportional hazardregression model
Hazard ratio(95% CI)
from instrumentalvariable analysis
Follow-up: 6 weeks
Antidepressantmonotherapy (ref:SGA monotherapy)
2.87 (1.10-7.49) 2.34 (0.41-13.30)
Prior mania 14.00 (8.99-21.78) 16.01 (9.58-26.77)Stimulant 1.86 (1.07-3.23) 1.86 (1.04-3.35)Oppositional defiant
disorder1.78 (1.09-2.90) 1.80 (1.07-3.04)
Residual (r) N/A 1.38 (0.21-8.89)
Follow-up: 8 weeks
Antidepressantmonotherapy
2.69 (1.10-6.60) 2.35 (0.51-10.75)
Stimulant 1.87 (1.11-3.15) 1.89 (1.09-3.29)Oppositional defiant
disorder1.85 (1.17-2.93) 1.88 (1.16-3.03)
Prior mania 12.47 (8.18-18.99) 13.93 (8.69-22.32)Residual (r) N/A 1.27 (0.25-6.40)
Follow-up: 12 weeks
Antidepressantmonotherapy
2.44 (1.09-5.46) 1.49 (0.34-6.58)
Stimulant 1.97 (1.19-3.25) 2.04 (1.21-3.46)Anticholinergic 0.25 (0.06-0.95) 0.17 (0.004-6.57)Oppositional defiant
disorder1.80 (1.16-2.79) 1.78 (1.12-2.83)
Prior mania 13.34 (8.91-19.96) 14.90 (9.41-23.59)Residual (r) N/A 2.11 (0.44-10.20)
Only statistically significant variables at p< 0.05 are included in thetable. Complete list of variables included in the models was as follows:demographics (age category, gender, race, state, number of physicians inthe ZIP codes), proxy measurements of severity (duration of disease, priorhospitalization), Medicaid eligibility groups (foster care, TemporaryAssistance to Needy Families), comorbidity (substance abuse disorder,attention-deficit/hyperactivity disorder, oppositional defiant disorder, anx-iety, adjustment disorder, psychotic disorder, prior mania), comedications(stimulant, sedative, hypnotic, anticholinergic, psychotherapy, SGA, moodstabilizer).
Table 4. Cox Proportional Hazards RegressionAnalysis Results (Antidepressant Monotherapy vs.
Mood Stabilizer Monotherapy)
Variables
Hazard ratio(95% CI) from
conventional Coxproportional hazardregression model
Hazard ratio(95% CI) frominstrumental
variable analysis
Follow-up: 6 weeks
Antidepressantmonotherapy (ref:mood stabilizermonotherapy)
1.41 (0.52-3.80) 1.17 (0.24-5.57)
Prior mania 17.80 (10.29-30.81) 24.06 (11.32-51.15)Residual (r) N/A 1.34 (0.23-7.67)
Follow-up: 8 weeks
Antidepressantmonotherapy
1.68 (0.67-4.21) 1.32 (0.30-5.84)
Anticholinergic 3.73 (1.14-12.16) 3.84 (0.88-16.69)History of mood
stabilizer2.21 (1.17-4.20) 2.30 (0.96-5.53)
Prior mania 18.16 (10.59-31.15) 24.24 (11.64-50.44)Residual (r) N/A 1.56 (0.29-8.40)
Follow-up: 12 weeks
Antidepressantmonotherapy
1.44 (0.63-3.29) 1.19 (0.28-5.13)
History of moodstabilizer
1.90 (1.02-3.55) 1.95 (0.83-4.60)
Prior mania 17.74 (10.42-30.20) 23.27 (11.54-46.95)Residual (r) N/A 1.45 (0.25-8.33)
Only statistically significant variables at p < 0.05 are included in thetable. Complete list of variables included in the models was as follows:demographics (age category, gender, race, state, number of physicians inthe ZIP codes), proxy measurements of severity (duration of disease, priorhospitalization), Medicaid eligibility groups (foster care, TemporaryAssistance to Needy Families), comorbidity (substance abuse disorder,attention-deficit/hyperactivity disorder, oppositional defiant disorder, anx-iety, adjustment disorder, psychotic disorder, prior mania), comedications(stimulant, sedative, hypnotic, anticholinergic, psychotherapy, history ofsecond generation antipsychotics, history of mood stabilizers).
ANTIDEPRESSANTS ASSOCIATED WITH MANIC SWITCH IN CHILDREN 557
-
risk of manic switch were not observed when antidepressant
monotherapy was compared with mood stabilizer monotherapy
(HR = 1.41 [95% CI: 0.523.80]) in our study. The finding could beexplained by the slower and weaker antimanic effect of mood
stabilizers compared with SGA (Delbello et al. 2006; Macmillan
et al. 2008; Pavuluri et al. 2010; Geller et al. 2012), and also by the
relatively small sample available for the comparison between MS
and antidepressant monotherapy recipients.
Both mood stabilizers and SGA are recommended for acute and
prophylactic treatment of the manic phase. Therefore, antimanic
medications (mood stabilizers and SGA) are believed to treat or prevent
an antidepressant-induced manic switch when antidepressantSGA/
mood stabilizer combination therapy is used. Literature suggests that
concomitant therapy with a mood stabilizer may reduce antidepressant-
induced manic switch (Ghaemi et al. 2003). Our analysis confirmed
that the combination of antidepressant and SGA/mood stabilizer has a
comparable risk of manic switch as SGA and mood stabilizer.
Our study is the first that assessed the risk of manic switch in
children and adolescents with bipolar depression, and it is also the
first head-to-head comparison study between antidepressant
monotherapy and polytherapy and their alternatives. Given that
making such comparisons in children using an experimental design
is highly unlikely because of ethical concerns, an observational
study such as this can provide valuable data for clinical practice.
Despite these advantages, existence of unobserved confounders
is always a concern in observational studies, regardless of how
refined the statistical methods and adjustment of the confounding
factors are. Although particular patient characteristics were taken
into account by adjusting for clinical and sociodemographic vari-
ables, geographic location, comorbidities, and past use of somatic
and psychotropic medications, data on some potentially important
confounding variables, such as responsiveness to the previous
treatment, were unavailable. Literature suggests that responsive-
ness to previous psychopharmacotherapy is an important predictor
of the risk of manic switch associated with an antidepressant
(Salvadore et al. 2010). It is likely that there is a severity difference,
and that patients who did not respond well to mood stabilizer and
SGA were switched to antidepressants. To test the robustness of the
conventional Cox proportional hazards model for possible unob-
served confounding, the analysis was conducted again using an IV
approach. The statistical insignificance of the residual r in the IV
analysis probably implies that unobserved confounding was not a
concern in the three models. Hence, the conventional Cox pro-
portional hazards model used in the main analysis might provide
sufficient statistical justification for the association between psy-
chotropic treatment and the risk of manic switch.
Another concern about the studies of manic switch is the lack of
agreement on the duration of follow-up (Salvadore et al. 2010).
Ideally, in order for results to be comparable across studies, a single
a priori definition of the time frame (e.g., 6 weeks) from the be-
ginning of antidepressant treatment in patients experiencing a de-
pressive episode, is required. Our present lack of consensus
regarding temporal criteria may dilute the biological underpinnings
of this phenomenon, because subjects who develop affective switch
within very different time frames from the start of antidepressant
treatments are considered equivalent. This methodological issue
has been emphasized by a task force of the ISBD (Grunze 2008). To
test the robustness of our findings against the different definitions of
switching, and to understand the effect of possible misclassifica-
tion, we conducted a sensitivity analysis by extending the follow-up
period from 6 weeks to 8 and 12 weeks. The sensitivity analysis
confirmed the higher risk of manic switch with antidepressant
monotherapy versus SGA monotherapy.
In addition to the two main concerns that have been addressed in
the sensitivity analysis, our study has other limitations because of
the nature of claims data. For example, prescription claims for
antidepressants, SGAs, and mood stabilizers were captured and
deemed bipolar depression treatment without documented indica-
tions from physicians notes. To ensure that those medications were
prescribed to treat bipolar depression, other common indications
for prescribing SGA or mood stabilizers (epilepsy, schizophrenia)
were removed from the cohort, and a strict rule requiring initiation
of the antidepressant within 30 days of depression diagnosis was
also applied. Also, bipolar depression cases and manic switch
events were identified based on ICD-9 diagnosis codes rather than
Table 5. Cox Proportional Hazards RegressionAnalysis Results (Antidepressant Polytherapy
vs. SGAMood Stabilizer Polytherapy)
Variables
Hazard ratio (95% CI)from conventionalCox proportionalhazard regression
model
Hazard ratio(95% CI)
from instrumentalvariable analysis
Follow-up: 6 weeks
Antidepressantpolytherapy (ref:SGA polytherapy)
1.61 (0.90-2.89) 1.23 (0.52-2.89)
Prior mania 10.96 (8.36-14.37) 11.33 (8.48-15.12)Residual (r) N/A 1.44 (0.58-3.59)
Follow-up: 8 weeks
Antidepressantpolytherapy
1.70 (0.97-2.98) 1.22 (0.54-2.76)
History of SGA 1.39 (1.01-1.91) 1.36 (0.97-1.92)Prior mania 10.51 (8.10-13.63) 10.85 (8.24-14.28)Residual (r) N/A 1.22 (0.64-3.75)
Follow-up: 12 weeks
Antidepressantpolytherapy
1.17 (0.71-1.92) 0.69 (0.32-1.49)
Prior mania 9.37 (7.35-11.96) 9.68 (7.46-12.56)Residual (r) N/A 2.03 (0.88-4.68)
Only statistically significant variables at p < 0.05 are included in thetable. Complete list of variables included in the models was as follows:demographics (age category, gender, race, state, number of physicians inthe ZIP codes), proxy measurements of severity (duration of disease, priorhospitalization), Medicaid eligibility groups (foster care, TemporaryAssistance to Needy Families), comorbidity (substance abuse disorder,attention-deficit/hyperactivity disorder, oppositional defiant disorder, anxiety,adjustment disorder, psychotic disorder, prior mania), comedications (stimu-lant, sedative, hypnotic, anticholinergic, psychotherapy, SGA, mood stabilizer).
SGA, second-generation antipsychotic.
Table 6. Association between Instrumentsand Treatment Cohorts
Treatment groups Comparison groups F statistics R2
Antidepressantmonotherapy
SGA monotherapy 149 0.28
Antidepressantmonotherapy
mood stabilizermonotherapy
150 0.40
Antidepressantpolytherapy
SGA-mood stabilizerpolytherapy
285 0.27
SGA, second-generation antipsychotic.
558 BHOWMIK ET AL.
-
structured clinical evaluation using depression and mania rating
scales. To negate possible misclassification of bipolar cases, a strict
algorithm was applied, and only patients who had had a minimum
of three bipolar disorder diagnoses were included in the analysis.
Manic switch associated with medication use is an emergent, one-
time event that cannot be ascertained by repeated coding; therefore,
misclassification of outcome caused by misdiagnosis or miscoding
cannot be completely ruled out. However, there is no practical
reason to believe that misclassification of disease in the claims data
would have affected treatment groups differently and, therefore, it
should not affect the studys conclusions.
Lastly, subcategories and individual drugs within the broad an-
tidepressant class could have varying degrees of risk of manic switch.
Tricyclic antidepressants (TCA) have been reported to have higher
risk of manic switch than newer antidepressants, such as SSRIs
(Salvadore et al. 2010). However, in our study cohort, *90% ofchildren and adolescents in the antidepressant monotherapy group
were on an SSRI antidepressant. It would be valuable, in future
analysis, to further assess the relative risk between individual SSRI
antidepressants in terms of manic switch.
Conclusions
In conclusion, antidepressant monotherapy was associated with
an increase in the risk of short-term manic switch compared with
SGA monotherapy. However, a similar association was not found
between antidepressant monotherapy and mood stabilizer mono-
therapy, or between antidepressant polytherapy and SGAmood
stabilizer combination. Overall, the study findings support the
current guidelines that antidepressant monotherapy should be al-
ways avoided, because of its potential for causing manic switch
Clinical Significance
Our study is the first that assessed the risk of manic switch in
children and adolescents with bipolar depression, and it is also the
first head-to-head comparison study between antidepressant
monotherapy, and combinations and their alternatives. Given that
making such comparisons in children using an experimental design
is highly unlikely because of ethical concerns, observational studies
such as this can provide valuable data for clinical practice.
Disclosures
No competing financial interests exist.
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Address correspondence to:
Hua Chen, MD, PhD
Department of Pharmaceutical Health Outcomes and Policy
College of Pharmacy
University of Houston
1441 Moursund St.
Houston, TX 77030
E-mail: [email protected]
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