Abstract
The present study examined the prospective relationship between obsessive–compulsive and depressive symptoms during a multimodal treatment study involving youth with obsessive–compulsive disorder (OCD). Participants included fifty-six youth, aged 7–17 years (M = 12.16 years) who were enrolled in a two-site randomized controlled pharmacological and cognitive behavioral therapy treatment trial. Obsessive–compulsive severity was measured using the Children’s Yale-Brown Obsessive–Compulsive Scale, and depressive symptoms were rated using the Children’s Depression Rating Scale-Revised. Multi-level modeling analyses indicated that, on average over the course of treatment, variable and less severe obsessive–compulsive symptoms significantly predicted a decrease in depressive symptoms. Additionally, week-to-week fluctuations in OCD severity did not significantly predict weekly changes in depressive symptom severity. Level of baseline depressive symptom severity did not moderate these relationships. Findings suggest that when treating youth with OCD with co-occurring depression, therapists should begin by treating obsessive–compulsive symptoms, as when these are targeted effectively, depressive symptoms diminish as well.
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Acknowledgments
This research was supported by grant 5UO1 MH078594 from the NIMH. The authors thank the study coordinators, all staff members who contributed to data collection, the families for their participation, and Drs. Ayesha Lall, Jane Mutch and Omar Rahman for their contribution to the study interventions.
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Appendix: Additional Description of MLM design
Appendix: Additional Description of MLM design
Each model throughout the analysis produces a −2 log likelihood (−2LL). This is a nonstandardized number that shows the amount of overall variance there is to be explained. With each additional model, the −2LL is expected to decrease, which means the model is improving. The Bayesian Information Criterion (BIC) serves a similar purpose as the −2LL, but in addition to denoting the amount of overall variance to be explained, it also takes into account the number of parameters that are being utilized in the model. The BIC is also expected to decrease with each subsequent model. Standardized (Z-score) parameterizations were used for all models, enabling comparison between predictors. This puts each parameter in a standard deviation scaling, where an estimate of 1 is interpreted as a one standard deviation change in the dependent variable (depressive symptoms).
Unconditional Means Model (UMM)
The Unconditional Means Model (UMM) is the worst fitting model, which is used to investigate whether there is significant between and within subject variance to be explained in depression severity. The between intercept and within residual were .650 (p < .001) and .361 (p < .001) respectively, denoting additional variability to be explained by further analysis. The −2 Log Likelihood (−2LL) for the unconditional means model (null model) was 1216.868.
Model A- Linear Time
Depressive symptoms over the course of treatment were estimated to identify any significant trajectories of depression that need to be controlled for in any subsequent modeling. When testing a linear trend in time, the model improved with a −2LL decreasing from 1216.868 in the null model to 1160.300 in the new model (χ² (1, N = 55) = 56.57, p < .001). Due to the uniformity of the way time was modeled across subjects, the average linear growth trend could still be modeled but not appropriately tested for effect size (i.e., no between subject variability). However, to enhance interpretation, a between-subjects linear growth model was still estimated in a separate analysis. On average, a significant negative slope in depressive symptomology was observed (p < .001), with significant positive variability in this slope (p < .001) that suggests a portion of the sample saw a much smaller decrease in depressive symptoms over time than on average. Linear time explained a substantial amount of the Random Effects (21.1 %). Table 1 does not include the between-subjects linear growth model that was estimated to enhance interpretability.
Model B- Quadratic Time
The next model tested a quadratic trend in depressive symptoms after orthogonalizing from any linear trends, which was done in order to minimize multicollinearity by controlling for linear time. The −2LL decreased once again from 1160.300 in the linear model to 1144.758 in the quadratic model (χ² (1, N = 55) = 15.54, p < .001). Similarly to the linear model, a between-subject quadratic growth model (nested within the negative linear slope described above) was estimated to increase interpretability but found a non-significant positive quadratic growth trend (p = .650). However, significant positive quadratic variability in slope was observed (p < .01). The quadratic model explained an additional 10.9 % of the within subject variance. However, after the addition of the best fitting error structure in Model F, the quadratic effect was no longer significant and thus will not be interpreted further. To summarize the growth modeling described above, on average, depressive symptom severity decreased uniformly across treatment (between subject linear slope). A few subjects saw much shallower linear decrease in depressive symptoms over time (within subject linear).
Model C- Age
A static covariate of age was nested within the linear and quadratic models and the age model improved the −2LL from 1144.758 to 1132.401 (χ² (1, N = 55) = 12.36, p < .001). For the Fixed Effects, age accounted for an additional 22.6 % of the variance. The beta weight for this model after the adjusted error structure was .339 (p < .001) indicating that a one standard deviation increase in age predicted a .339 standard deviation increase in depressive symptoms on average.
Model F- Best Fitting Error Structures
The initial six models were conducted under the SPSS default assumptions for Random and Repeated Error Structures (independence of errors and variance components). The final −2LL for Model E was 1015.693 and thus, all possible error structure combinations, which theoretically were appropriate for this study design, were tested. The best fitting random error structure identified was variance components (assumes homoscedasticity of the intercept-slope relationship throughout the study). The best fitting repeated measures error structure identified was autoregressive error (AR1), which assumes homoscedasticity, and inter-occasion correlations that are reduced, exponentially, by the time lag between them. Using these two error structures, our final −2LL was reduced to 1007.113, which represented the best fitting model compared to any other combination tested. The final model with the best fitting error structures did not alter the pattern of significance (with the exception of the random effect of quadratic time which became insignificant), but was a significant improvement from the unadjusted final model (χ² (1, N = 55) = 8.58, p < .01).
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Meyer, J.M., McNamara, J.P.H., Reid, A.M. et al. Prospective Relationship Between Obsessive–Compulsive and Depressive Symptoms During Multimodal Treatment in Pediatric Obsessive–Compulsive Disorder. Child Psychiatry Hum Dev 45, 163–172 (2014). https://doi.org/10.1007/s10578-013-0388-4
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DOI: https://doi.org/10.1007/s10578-013-0388-4