Abstract: How Much of the Sexual-Orientation-Related Disparities in Youth Mental Health Can be Explained By Experience of Victimization? a Mediation Analysis with Causally Defined Effects (Society for Prevention Research 22nd Annual Meeting)

483 How Much of the Sexual-Orientation-Related Disparities in Youth Mental Health Can be Explained By Experience of Victimization? a Mediation Analysis with Causally Defined Effects

Schedule:
Friday, May 30, 2014
Lexington (Hyatt Regency Washington)
* noted as presenting author
Trang Quynh Nguyen, MS, PhD Candidate, Johns Hopkins Bloomberg School of Public Health, Washington, DC
Kerith Conron, ScD, Research Scientist, The Fenway Institute, Boston, MA
Katherine E. Masyn, PhD, Assistant Professor, Harvard University, Cambridge, MA
Introduction

This study assessed to what extent sexual-orientation-related disparities in youth mental health are associated with disproportionate exposure to violence. We evaluated Pearl/VanderWeele’s causally defined direct and indirect effects, extending Muthen’s ordinal-mediator-binary-outcome method to allow multiple mediators.

Methods

We used Massachusetts Youth Risk Behavior Survey pooled 2003-2011 data to assess the contribution of violence to mental health differences between sexual minority (lesbian/gay, bisexual, or unsure of sexual identity) and heterosexual youth, separately for males and females. Mediation analysis was conducted via a structural probit model with sexual orientation, binary/ordinal mental health outcomes (depression, non-suicidal self-injury, suicidal thought, plan, attempt, and attempt with injury) and binary/ordinal mediators (threatened with weapon, physical fights, injured in fights, hurt on a date, forced sex), controlling for age, race/ethnicity and year.

Direct, indirect and total effects (DE, IE and TE) were defined from a causal inference perspective: DE compares risk of outcome given a minority status and given heterosexual status, both with mediators at heterosexual group levels [PX0 = P(Y | minority, M(heterosexual)); P00 = P(Y | heterosexual, M(heterosexual))]. IE compares risk given minority status and mediators at minority group levels [PXX = P(Y | minority, M(minority))] and at heterosexual group levels [PX0]. TE compares PXX and PX0. To compute P00, PX0 and PXX, we adapted Muthen’s formula for the Y*-rescaling factor (for the single mediator case) to incorporate the mediator residual correlation matrix. We calculated DE, IE and TE on multiplicative (risk ratio – RR) and additive (risk difference – RD) scales: RRTE = RRDE * RRIE; RDTE = RDDE + RDIE. We computed the proportion of RD explained by mediation PE = RDIE/RDTE. Confidence intervals (CI) were bootstrapped.

Results

RRTE are statistically significantly greater than 1, indicating greater risk for sexual minorities. For females, RRDE (indicating differential risk when “fixing” violence exposure at heterosexual group levels) are non-significant for depression comparing lesbian and unsure youth to heterosexuals. For males, RRDE are non-significant for all outcomes for unsure youth, and for suicide attempt with injury for all minority groups. RRIE (indicating risk increase for sexual minorities due to differential violence exposure) range from 1.2 to 1.7 for females, 1.4 to 4 for males, all 95% CI greater than 1. PE range from 32% to 78% for females, 41% to 100% for males, all 95% CI not including zero.

Conclusion

Sexual orientation disparities in depression and suicidality are partially due to physical and sexual violence. Effective interventions are needed.