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Depression is associated with the onset of type 2 diabetes. A systematic review and meta-analysis of observational studies, controlled trials, and unpublished data was conducted to examine the association between depression and insulin resistance (IR).
Medline, EMBASE, and PsycINFO were searched for studies published up to September 2011. Two independent reviewers assessed the eligibility of each report based on predefined inclusion criteria (study design and measure of depression and IR, excluding prevalent cases of diabetes). Individual effect sizes were standardized, and a meta-analysis was performed to calculate a pooled effect size using random effects. Subgroup analyses and meta-regression were conducted to explore any potential source of heterogeneity between studies.
Of 967 abstracts reviewed, 21 studies met the inclusion criteria of which 18 studies had appropriate data for the meta-analysis (n = 25,847). The pooled effect size (95% CI) was 0.19 (0.11–0.27) with marked heterogeneity (I2 = 82.2%) using the random-effects model. Heterogeneity between studies was not explained by age or sex, but could be partly explained by the methods of depression and IR assessments.
A small but significant cross-sectional association was observed between depression and IR, despite heterogeneity between studies. The pathophysiology mechanisms and direction of this association need further study using a purposively designed prospective or intervention study in samples at high risk for diabetes.
Depression is at least twice as common among those with diabetes compared with the general population (1) and is associated with adverse effects on diabetes outcomes including suboptimal glycemic control (2), complications (3), and higher rates of mortality (4,5). Depression appears to be present even at the prediabetes stage of the type 2 diabetes (T2DM) continuum with pooled data suggesting that depression in the nondiabetic population is independently associated with a 37–60% increased prospective risk of developing T2DM (6).
Insulin resistance (IR) is a prediabetes stage. There have now been several studies examining the association between depression and IR. These studies have had mixed findings. The aim of this review is to conduct a systematic synthesis and a meta-analysis of the evidence for the association between depression and IR. A positive association would increase the plausibility of a biological link between depression and diabetes and suggest a potentially modifiable target for the prevention of T2DM.
Our systematic review and meta-analysis was conducted according to Preferred Reporting Items for Systematic Reviews and Meta-Analyses (PRISMA) guidelines (7).
The following electronic libraries—MEDLINE (1948 to September 2011), EMBASE (1947 to September 2011), and PsycINFO (1806 to September 2011)—were searched to identify relevant studies. The search items were based on established terminology using Cochrane definitions where possible and were “diabetes,” “depression,” “insulin resistance,” and “insulin sensitivity” (Supplementary Table 1). The titles and/or abstracts were reviewed to exclude any clearly irrelevant studies. The full texts of the remaining studies were then retrieved and read in full by two authors (C.K. and N.S.) independently to determine whether the studies met inclusion criteria. Disagreement was resolved by a third author (K.I.) who independently examined the studies. The reference lists of studies that examine the topic of interest were checked for additional publications while corresponding authors were contacted for additional information on published and unpublished studies.
Abstracts were considered eligible for full manuscript data extraction if the study met all the following criteria: a) they reported an association between depression and IR (including its reverse measure, low insulin sensitivity); b) sample consisted of adults (≥18 years of age); and c) the design was cross-sectional, observational, or a randomized controlled trial. Studies that excluded patients with depression at baseline or consisted solely of patients with diabetes (or where it was not possible to separate diabetic and nondiabetic participants) were not included.
Using a standardized data extraction sheet, the following information (if available) was extracted and recorded from studies: authors; year of publication; country of origin; study design; total sample size of nondiabetic participants; age; sex; methods of IR assessment; methods of depression assessment; and type of confounders. Authors were contacted to clarify whether prevalent cases of diabetes were excluded at baseline. An attempt to retrieve missing or incomplete data in the published study was made by e-mail to at least two coauthors on at least two occasions. If multiple risk estimates were presented in a given manuscript, the unadjusted estimate was selected for the primary meta-analysis as some studies were adjusted for prominent confounding variables, such as family history and adiposity, while others were not, rendering a direct comparison of estimates to be questionable. Reporting unadjusted estimates also reduces the bias of selective reporting of adjusted estimates in primary studies and the potentiality of overadjustment with multiple confounders, which may also be on the causal pathway for the effect of depression on IR, such as obesity (8). Studies written in a foreign language were translated by mental health professionals fluent in that language.
There is no consensus as to the best standardized method for assessing the quality of observation studies, and the PRISMA guidelines for randomized controlled trials (7) and Meta-analysis Of Observational Studies in Epidemiology (MOOSE) guidelines for observational studies in epidemiology (9) were used to examine the quality of the studies. These include adequacy of study design (prospective cross-sectional, observational, and randomized controlled trial with an adequate control group); recruitment of sample; ascertainment of depression and IR; and control for cofounding variables, such as age, sex, socioeconomic status, and BMI. The quality of the studies was not summarized with a score, as this approach has been criticized for allocating equal weight to different aspects of methodology (10), but a formal assessment of the risk of bias and strength of evidences according to the Agency for Healthcare Research and Quality (AHRQ) guidelines was conducted (11). A study was considered to be of high quality if the study design was prospective in nature; consecutive or random sampling method was used; the ascertainment of depression was through a structural diagnostic interview based on the ICD (12) or the DSM (13); and cofounders for diabetes and depression (age, sex, ethnicity, BMI/waist circumference, socioeconomic status, physical activity) were accounted for.
Meta-analyses were carried out using Stata 10.1 and 11.1 (14,15), with user-contributed commands for meta-analyses: metan, metainf, metabias, metatrim and metareg (16). The Cohen d approach was used to calculate the primary effect size, as it allows data from different platforms to be combined without the use of normalization and can be converted from different effect sizes. It was calculated for the majority of the datasets by the mean difference in IR between depressed and nondepressed groups divided by the pooled SD. The SE of each study’s standardized effect estimate was calculated from the estimated effect and the study’s group sizes according to a formula provided by Cooper and Hedges (17). If Pearson correlation coefficient (rρ) was reported instead, it was transformed into Cohen d using Cohen’s conversion formula (1988): . The variance was calculated by Vd = 4Vr /(1-r2)3 where Vr is the variance of rp. The same conversion was applied to Spearman correlation coefficients (rs) since rρ is equivalent to rs using rank data or is slightly smaller if the data are binomial distributed (18). In one study (19), the z statistic of a Mann-Whitney U test was used to transform z to r using Fischer transformation (20) and then converting r to Cohen d using the above formula. Results reported in odds ratios were transformed in Cohen d using the method recommended by Borenstein et al. (21), . The associated variance of d would then be and the .
The effect sizes and SEs of the studies were pooled using random-effects models. The random-effects meta-analysis models were chosen as heterogeneity is expected given the differences in study populations and procedures. The assumption of homogeneity of true effect sizes was assessed by the Cochran Q test (22), and the degree of inconsistency across studies was calculated I2 (23). I2 describes the percentage of total variation across studies that is due to heterogeneity rather than sampling error and ranges between 0% (no inconsistency) and 100% (high heterogeneity) with values of 25, 50, and 75% suggesting low, moderate, and high heterogeneity (23). A priori meta-regression analysis was then performed to assess whether conclusions were sensitive to restricting studies to subgroups that might modify the effect size: i) mean age; ii) sex; iii) method of depression assessment; and iv) method of IR assessment. Random-effects models were used to allow for the residual heterogeneity among attrition rates, which were not modeled by the explanatory variables (24). A secondary analysis of adjusted and corresponding unadjusted data when available was also conducted using the random-effects models.
Sensitivity analyses were conducted to weigh up the relative influence of each individual study on the pooled effect size using STATA’s user-written function, metainf (16). The presence of publishing bias for the hypothesis of an association between depression and IR was assessed informally by visual inspections of funnel plots (25) and corroborated by Begg adjusted rank correlation (26) as implemented in metabias. The nonparametric “trim and fill” method was also used to estimate the number of hypothetical studies that were missing due to possible publication bias and was implemented in STATA’s user-written command, metatrim (16). It is a sensitivity analysis since it relied on strong symmetrical assumption and could be influenced in the presence of strong between-group heterogeneity (27).
The flowchart is shown in Fig. 1. The literature search resulted in 962 studies. After review of their titles and abstracts, 38 studies met the inclusion criteria and were retrieved for full text. Of these, 21 studies were excluded from the systematic review as they no longer met the inclusion criteria. The search for additional studies among the reference lists of included articles yielded five more studies, with four meeting inclusion criteria. A total of 21 studies were included in the systematic review, and the extracted data are summarized in Table 1.
Three studies were excluded from the meta-analysis; one study was published as an abstract (28) and did not include any information about sampling method, baseline clinical characteristics of the sample population, and depression measure. The data of two large cohort studies were presented in quartiles (29,30), and raw data were not available to generate a standardized effect size. This resulted in 18 studies being included in the meta-analysis.
Upon further examination, one study was found to be made up of two separate studies using two different study populations (31), which were therefore separated into two different datasets. The sample for six studies were separated into normal/impaired glucose tolerance (32,33) and men/women (19,34–36), yielding an additional six datasets. The total number of datasets in the meta-analysis was therefore 25.
Of the 25 datasets include in the meta-analysis, one was a prospective longitudinal cohort study (37), six were case-control studies (31,38–41), and 18 were cross-sectional studies (19,32–36,42–47). Four datasets were based on clinical diagnosis using DSM-IV, six used semistructured diagnostic interviews, and 15 used self-report depressive scales. IR was reported in 18 datasets while insulin sensitivity was measured in seven datasets. Descriptive data from the datasets are summarized in Table 1.
A total of 25 datasets (n = 25,847) provided unadjusted data on the association between depression and IR in adults without diabetes. A random-effects meta-analysis revealed a small pooled estimate of the mean standardized effect sizes (d = 0.19 [95% CI: 0.11–0.27]) (Fig. 2), with the effect sizes ranging from d = -0.56 to d = 1.37. Heterogeneity between the studies was statistically significant (Q (24) = 134.83, P < 0.0001) and large in magnitude (I2 = 82.2%).
A series of random-effects subgroup analyses and meta-regression was conducted to examine whether the association between depression and IR varied across demographic groups and the methods of depression and IR assessments. Age (β = -0.002 per year, t = -0.50; P = 0.62) or sex (β = 0.0006, t = 0.33; P = 0.74) did not significantly change the observed association between depression and IR. With the random-effects model, a much greater effect size was observed for diagnostic interviews than self-report measures (0.46 [0.22–0.71] vs. 0.13 [0.05–0.21]) and the difference was statistically significant in the meta-regression (z = 2.22, P < 0.0001). A larger effect size with insulin sensitivity as an IR measure was found in comparison with studies using homeostasis model assessment of insulin resistance (HOMA-IR) or HOMA2-IR test (0.32 [0.12–0.53] vs. 0.17 [0.08–0.26]), and the difference was also significant (z = 4.70, P < 0.0001). The observed association between depression and IR remained statistically significant in all subgroup analyses.
Of the 17 datasets with confounders being included, three studies were excluded from the secondary analysis. Depression and IR were not the main outcome of interest in one study (40) and thus, its association was not adjusted for the confounder being measured, while two studies presented their data in quartiles (45,46) and raw data were not available to generate a standardized effect size. This resulted in 14 datasets being included in the random-effects secondary meta-analysis. The estimate of the mean standardized effect sizes was 0.11 (0.04–0.17) for the unadjusted datasets (n = 22,545) and 0.02 (−0.02 to 0.07) for the adjusted datasets (n = 21,826) (Fig. 3).
The robustness of the estimate was examined by sequentially removing each study and reanalyzing the remaining datasets. The estimated effect sizes ranged from d = 0.14 to d = 0.21, with all effect sizes being significantly different from 0, suggesting that the significant effect size is not determined by a single study. Sensitivity analysis for the secondary analysis also revealed that no single study has substantial influence on the effect size for the adjusted and unadjusted datasets.
There was some evidence of publishing bias regarding studies of depression and IR from visual inspection of the funnel plot (Supplementary Fig. 1) and the Begg coefficient (z = 2.22, P = 0.027). The trim and fill sensitivity method imputed estimates from nine hypothesized negative unpublished studies. The “publication bias” corrected effect size attenuated to 0.07 (−0.02 to 0.16), and this was not significant (P = 0.117).
Given that most studies were cross-sectional and all were observational, the overall risk of bias was medium to high and the study quality was fair. The overall magnitude of association was small and there was substantial heterogeneity between studies, but the estimate was precise as reflected by the narrow CIs and the magnitude of association for diagnostic criteria for depression was larger than for self-report depression measures. This suggests that the strength of evidence is low to moderate.
To our knowledge, this study represents one of the first systematic reviews and meta-analysis of the evidence for an association between depression and IR using data from observational studies, controlled trials, and unpublished data. A small but significant association between depression and IR was observed that was attenuated in analyses adjusted for body weight and other confounders. The magnitude of the association increased when a diagnostic interview for depression was used to define depression or insulin sensitivity was a measure of IR.
The primary strength of this meta-analysis is the expansive literature search but it has several limitations, mainly stemming from the quality of the included studies as summarized in Table 1. There was substantial evidence of heterogeneity and potential publication bias. The observed funnel plot asymmetry could be partly explained by the heterogeneity in depression measure as clinical/diagnostic interviews were the depression assessments in five out of six datasets with a sample size below 100. The random-effects model was chosen to account for heterogeneity and the association remained significant in all subgroup analyses. There was substantial evidence of heterogeneity and potential publication bias.
A further limitation of the study is the inconsistent reporting of results, making it necessary to convert different effect sizes into a common one. The conversion of correlation and odds ratio into Cohen d rely on the assumptions that the distribution of the underlying trait is continuous (21). Association also does not imply causation and the temporal relationship between depression and IR could not be delineated since the present meta-analysis is mainly based on cross-sectional data. Nearly every individual study was a secondary analysis of a study designed to test a different primary hypothesis and this inevitably will result in some measurement bias and residual confounding. The strength of systematic reviews is that by systematically identifying these limitations, future designs can be improved.
These results suggest that the association between depression and diabetes may start at an earlier stage since prevalent cases of diabetes were excluded from this study and IR is on the casual pathway of developing T2DM. This is supported by other recent reviews (6,48) and a recent meta-analysis, which provides evidence for a bidirectional association between depression and metabolic syndrome (49) with hyperglycemia being one of the diagnostic criteria of metabolic syndrome. These results indicate a small but significant association between depression and prediabetes or other biomarkers of glucose dysregulation.
There are several possible pathophysiological mechanisms that may explain the observed relationship. Depression is associated with disruption to the hypothalamic-pituitary adrenal axis, causing an increase in cortisol and catecholamine, hormones responsible for antagonizing the hypoglycemic effects of insulin and resulting in IR (50). People with diagnostic depression have increased levels of inflammation (51), and psychological stresses have been shown to activate the innate inflammatory response with chronic cytokinaemia leading to IR and β-cell apoptosis, antecedents to the development of T2DM (52). Depression can also have influences on lifestyle behaviors associated with diabetes risk factors such as dietary intake, exercise, and medication adherence (53,54). Findings from the secondary analysis using data adjusted for confounders, such as obesity, might explain some of the observed associations between depression and IR, although it should be interpreted with caution as body weight has been postulated to be on the casual pathway for depression and IR, raising the potentiality of overadjustment.
The type of depression assessment makes a substantive difference in the observed association between depression and IR, which may in part reflect a greater sensitivity of clinical interviews in detecting depression. Self-report measures such as the Center for Epidemiologic Studies Depression Scale (CES-D) have been validated in epidemiological studies (55) but uncertainty remains in regards to their relation to clinically diagnosed depression. Estimates of depression have been suggested to differ depending on the use of dimensionally verses categorically based depression assessment tools (56). The method at which IR is being measured also has an impact upon the finding. There are several different methods to measure depression and IR. The hyperinsulinemic-euglycemic clamp is currently the gold standard but is unsuitable for large-scale cross-sectional studies for practical reasons. Good correlation has been demonstrated between estimates from HOMA and euglycemic clamp (Rs = 0.88, P < 0.0001) (57), whereas the quantitative insulin sensitivity check index (QUICKI) has been suggested to be superior to HOMA-IR (58). Some studies have, however, shown that minimal model analysis from frequently sampled intravenous glucose tolerance tests underestimates insulin sensitivity (59).
This review suggests that it is now time to move from repeating cross-sectional studies to studies examining causal relationships. The ideal study design could either be a prospective design of patients potentially at high risk for T2DM (e.g., positive family history of diabetes); with or without diagnostic depression; matched for at least age, sex, obesity, and change in IR measured over time; or a randomized controlled trial in a sample of depressed patients testing whether intensive treatment of depression (pharmacological or psychological) leads to improvements in IR and other markers of glucose dysregulation. Further secondary analyses are unlikely to contribute further to the field unless there is adequate assessment of potential confounding.
This systematic review and meta-analysis contributes to the growing evidence of a small but persistent association between depression and the onset of T2DM.
C.K. receives salary support from the National Institute for Health Research Mental Health Biomedical Research Centre at South London, Maudsley National Health Service Foundation Trust, and King's College London.
No potential conflicts of interest relevant to this study were reported.
C.K., N.S., S.H.G., and K.I. designed the protocol with contributions from U.R. and M.T. C.K. and N.S. extracted the data while C.K. wrote the manuscript. D.S. supervised the statistical analysis. All authors reviewed and edited the manuscript.
The authors would like to thank An Pan, National University of Singapore; Jari Jokelainen, University of Oulu, Finland; Holly Syddall and Karen Jameson, MRC Lifecourse Epidemiology Unit, University of Southampton, UK, for providing further data to complete the meta-analysis, and Giovanni Cizza, National Institute of Diabetes and Digestive and Kidney Diseases; Michael Deuschle, Central Institute of Mental Health; Susan Everson-Rose, University of Minnesota; and Sue Pearson, University of Tasmania, for clarifying the methodology of their studies.
This article contains Supplementary Data online at http://care.diabetesjournals.org/lookup/suppl/doi:10.2337/dc12-1442/-/DC1.
The views expressed are those of the authors and not necessarily those of the National Health Service, the National Institute for Health Research, or the Department of Health.