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“To Avoid Evaluation, Withdraw”: Fears of Evaluation and Depressive Cognitions Lead to Social Anxiety and Submissive Withdrawal

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Abstract

We propose a cognitive model of social anxiety-related submission based upon psycho-evolutionary accounts of social anxiety and depression and present results of two studies supporting this model. We tested a confirmatory factor model consisting of three latent lower-order factors (fear of negative evaluation, fear of positive evaluation, and depressive cognitions), all of which load onto a single latent higher-order submissive cognitions factor. In essence, we propose that the symptoms associated with social anxiety and depression (in part) served adaptive functions for coping with social threats in the ancestral environment and that the cognitive symptoms associated with these disorders may function collectively as integrated components of a social anxiety-related submission mechanism. Confirmatory factor analysis indicated that the hypothesized model fit well. A score derived from the submissive cognitions factor correlated strongly with social anxiety-related measures and less strongly with measures of generalized anxiety/worry in Studies 1 and 2. Furthermore, this submissive cognitions score correlated in the expected direction with self-report measures of social comparison, negative affect, and positive affect in Study 2, and mediational analyses indicated that submissive cognitions may mediate the relationship between social comparison and submissive behaviors. Findings from both studies provide support for the proposed model.

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Notes

  1. The factor analysis of the BDI-II by Ward (2006) appears definitive in establishing the structure of the instrument. However, the best-fitting model has the function of partialling a general depressive mood from the cognitive items. Although Ward is correct that the so-called cognitive items also include responses related to affect, the BFNE and FPES also include affect-related information. Use of Ward’s model in our analyses would thus not only result in a model that might be too complex to be adequately estimated in our sample but also would involve treating the BDI-II items very differently than the items from the other measures.

  2. Results using the SIAS total score are available upon request and are substantively identical to the current results.

  3. The Guttman split-half coefficient was utilized to calculate the internal consistency of the GAD-Q-IV due to the structure of the GAD-Q-IV response scales (see Newman et al. 2002).

  4. We also calculated z-scores of the three SCS subscales (i.e., BFNE-S, FPES, and BDI-C scores) and summed these standardized subscale scores to derive a standardized SCS total score. This score is less complicated to calculate; it would therefore be useful to know whether it is essentially isomorphic with the estimated SCS factor score. Indeed, it was; in both samples, the standardized SCS score significantly predicted the estimated SCS factor score, accounting for more than 96% of the variance in the estimated SCS factor scores (both overall adjusted R 2s > .96). We used the SCS factor score because of its (theoretical) greater precision, but other researchers could use the standardized score with confidence.

  5. Estimated factor scores for the SCS lower-order factors were derived using the same general procedure utilized to derive SCS scores (see the Deriving a Submissive Cognitions Scale (SCS) Score section); we based our calculations on multiple regression analyses in which all items used to estimate the lower-order factor were used to predict the lower-order factor score. In each case, most of the variance of the lower-order factor score (all R 2s > .91) was predicted by the items. Subsequent analyses involving the SCS sub-dimensions used the estimated lower-order factor scores, calculated by weighting each item with its unstandardized regression coefficient obtained from the respective multiple regression analysis above.

  6. It should be noted that mediation cannot be truly demonstrated in cross-sectional (as opposed to longitudinal) designs, as such designs preclude the testing of temporal/causal patterns (e.g., see Kraemer et al. 2001). We include these analyses because mediational analyses conducted within cross-sectional samples can provide preliminary support for putative mediational relationships.

  7. Because the regression equations recommended by Baron and Kenny (1986) do not produce standardized regression coefficients, partial correlation (pc) coefficients were provided for comparison on a common metric.

  8. To examine whether the effect obtained in testing our hypothesized mediational model could be specific to certain sub-dimensions of submissive cognitions (FNE, FPE, or depressive cognitions), we tested three additional mediational models in which the estimated lower-order factor scores for (1) FNE, (2) FPE, and (3) depressive cognitions were included as separate mediator variables. The Social Comparison Rating Scale total score served as the predictor variable, and the Submissive Behavior Scale score served as the outcome variable in each of these models. Results from these additional mediational models were substantively identical to the results obtained from our hypothesized model (all Sobel’s zs > −4.68, all ps < .001), with all obtained effects in the expected directions. The fact that all models are consistent with the SCS model, but not as strong, indicates that the mediation effect is not due to only one of the lower-order factors. The results from these additional models are available upon request.

  9. If our model of social anxiety-related submission is to apply to participants with clinical levels of anxiety and depression, a significant number of participants displaying such symptoms must be present in the samples utilized in the present studies. We therefore examined our samples in light of cut score guidelines provided by Heimberg et al. (1992) and Beck et al. (1996). Heimberg et al. (1992) reported that a cutoff score of 34 on the SIAS correctly classified 82% of participants with social anxiety disorder and control participants, and this cutoff score was cross-validated by Brown et al. (1997). Across our samples, 25.4% (Study 1) to 32.4% (Study 2) scored at or above this cutoff. Moreover, 12.4% (Study 1) to 12.5% (Study 2) of participants obtained BDI-II scores indicating moderate depression, and 9.4% (Study 1) to 9.9% (Study 2) obtained scores indicating severe depression. These findings provide some support for the generalizability of our findings to clinical samples of socially anxious and depressed patients.

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  1. Justin W. Weeks

    Present address: Department of Psychology, Ohio University, Athens, OH, USA

Authors and Affiliations

  1. Adult Anxiety Clinic of Temple, Department of Psychology, Temple University, Weiss Hall, 1701 North 13th Street, Philadelphia, PA, 19122-6085, USA

    Justin W. Weeks, Richard G. Heimberg & Tejal A. Jakatdar

  2. Department of Psychology, Washington University, St. Louis, MO, USA

    Thomas L. Rodebaugh

  3. Department of Psychology, University of Houston, Houston, TX, USA

    Peter J. Norton

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Weeks, J.W., Rodebaugh, T.L., Heimberg, R.G. et al. “To Avoid Evaluation, Withdraw”: Fears of Evaluation and Depressive Cognitions Lead to Social Anxiety and Submissive Withdrawal. Cogn Ther Res 33, 375–389 (2009). https://doi.org/10.1007/s10608-008-9203-0

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