دانلود مقاله ISI انگلیسی شماره 38119
عنوان فارسی مقاله

افسردگی مادران و دستاوردهای درمان زیر یک مداخله شناختی رفتاری برای استرس پس از سانحه در کودکان پیش دبستانی

کد مقاله سال انتشار مقاله انگلیسی ترجمه فارسی تعداد کلمات
38119 2013 7 صفحه PDF سفارش دهید محاسبه نشده
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عنوان انگلیسی
Maternal depression and treatment gains following a cognitive behavioral intervention for posttraumatic stress in preschool children
منبع

Publisher : Elsevier - Science Direct (الزویر - ساینس دایرکت)

Journal : Journal of Anxiety Disorders, Volume 27, Issue January 2013, Pages 140–146

کلمات کلیدی
مدیران نتیجه - استرس پس از سانحه - رفتار درمانی شناختی - کودکان
پیش نمایش مقاله
پیش نمایش مقاله افسردگی مادران و دستاوردهای درمان زیر یک مداخله شناختی رفتاری برای استرس پس از سانحه در کودکان پیش دبستانی

چکیده انگلیسی

Abstract The evidence base for cognitive behavioral therapy (CBT) to treat child emotional and behavioral symptoms following exposure to trauma in youth is compelling, but relatively few studies are available on preschool children and on moderators of treatment outcomes. This paper examines maternal and child characteristics as moderators of posttraumatic stress (PTS) treatment outcomes in preschool children. Outcome data from a previously published randomized trial in three to six year old preschool children with diagnostic interview data from participating mothers were used. Hypotheses were tested via hierarchical linear modeling. Maternal depression was associated with higher initial child posttraumatic stress disorder (PTSD) symptoms, and was associated with increasing PTSD symptom trends at follow up suggesting potential child PTSD symptom relapse. Maternal PTSD symptoms similarly predicted differential child separation anxiety symptom change but not child PTSD symptom change. Targeting dyads with child PTSD symptoms and maternal depression or PTSD symptoms with enhanced interventions may be a useful strategy to improve treatment maintenance.

مقدمه انگلیسی

1. Introduction Research suggests that exposure to traumatic experiences can trigger a number of negative outcomes in youth and children (Carrión et al., 2002, Carrión et al., 2007 and Scheeringa et al., 2003). Research also indicates that these are evident even in very young children such that three to six year olds may experience posttraumatic stress (PTS) including the emotional and behavioral problems associated with the diagnosis of posttraumatic stress disorder (PTSD; Scheeringa et al., 2003). These symptoms include negative re-experiencing, avoidance, emotional numbing and hyper-arousal (APA, 1994). Fortunately, cognitive-behavioral therapy (CBT) for PTS in youth has been shown to be efficacious (Silverman et al., 2008). However, only three randomized trials have examined CBT for PTSD in young children (Cohen and Mannarino, 1996a, Deblinger et al., 2001 and Scheeringa et al., 2011a) and results suggest feasibility and efficacy in preschool (e.g., 3–6 years) children (i.e., results suggest reduction in rates of the diagnosis of PTSD, reduction of PTSD symptoms, and comorbid symptoms). In a review and meta-analysis of the child and adolescent PTS treatment literature, Silverman et al. (2008) noted that while CBT treatments appeared generally efficacious many youth are still symptomatic and very little work has been done examining potential moderators and predictors of treatment outcome. Indeed individual level CBT treatment data suggests wide variability in youth PTSD symptom change (Taylor & Weems, 2011). Kazdin (2007) defines an intervention moderator as a “characteristic that influences the direction or magnitude of the relation between the intervention and outcome” (p. 3) implying differential symptom change as a function of putative moderators. The Silverman et al. (2008) review highlights the importance of examining the role of parent characteristics in differential outcomes. Indeed, the results of their meta-analysis showed that including parents in the children's treatment did appear to enhance child anxiety and depressive symptom outcomes but did not appear to enhance child PTSD symptom outcomes. Cohen and Mannarino, 1996b and Cohen and Mannarino, 2000 have examined predictors of child PTS outcomes and indicated that the Parent Emotional Reaction Questionnaire was a strong familial predictor of treatment outcome at post treatment (Cohen & Mannarino, 1996b). Given the limited data on moderators of outcomes in youth with PTS, drawing more broadly from the child anxiety treatment literature provides additional support for the importance of maternal characteristics. Berman, Weems, Silverman, and Kurtines (2000) examined predictors of treatment outcomes of exposure based CBT with data from two outcome studies for childhood anxiety disorders (specific phobias, generalized, social and separation anxiety disorders, Silverman et al., 1999a and Silverman et al., 1999b). Parents’ self-ratings of depression at pre-treatment were associated with treatment failure, defined as not having ‘recovered’ (i.e., no longer meeting criteria for the DSM diagnostic criteria for the primary and targeted phobic or anxiety disorder)”. Children's comorbid diagnoses of depression, and depressive symptoms, as well as trait anxiety at pre-treatment were also associated with treatment failure. Age, income, and primary anxiety diagnosis were not predictors of success or failure in therapy. Southam-Gerow, Kendall, and Weersing (2001) also examined child and parent predictors of poor response in CBT treatment outcomes (i.e., not meeting criteria for any anxiety disorder versus still meets criteria for one anxiety disorder immediately after treatment or at 1 year follow up). Older age was associated with poor treatment response immediately following treatment and maternal depression was associated with poor response at 1 year follow up. Ethnicity, gender, family income, and a measure of therapeutic relationship were not associated with treatment outcome. It is important to note that none of these studies formally examined differential symptom change as a function of putative moderators (i.e., the studies either simply tested predictors of post assessment or follow up scores (i.e., Cohen and Mannarino, 1996b and Cohen and Mannarino, 2000) or compared those who did well versus those who did relatively poorly (i.e., Berman et al., 2000 and Southam-Gerow et al., 2001). The purpose of this study was to expand the childhood PTS treatment literature by examining maternal and child characteristics as moderators of PTS outcomes using data from a previously published randomized trial (Scheeringa, Weems, et al., 2011). Scheeringa, Weems, et al. (2011) randomly assigned 64 youth to either 12-session manualized CBT or 12-weeks wait list. In the randomized design the intervention group improved significantly more on symptoms of PTSD. After the waiting period, all participants were offered treatment. Effect sizes were large for PTSD symptoms and were maintained at a six-month follow up. Overall, findings suggested that CBT was feasible with preschool children and effective for treating PTS. Drawing from the extant literature, we predicted that maternal depression may negatively affect PTS outcomes. The extant research suggests maternal depression may impede treatment and/or treatment maintenance in child internalizing interventions (Berman et al., 2000 and Southam-Gerow et al., 2001). Similar findings exist in the disruptive behavior disorders treatment literature as well (Chronis et al., 2006 and Owens et al., 2003). Theoretically, offspring of depressed parents are at increased risk for developing anxiety disorders (see Colletti et al., 2009) and depressed mothers may have difficulty fostering the therapeutic process of maintaining treatment gains. Scheeringa and Zeanah (2001) have proposed theoretical models of the parent–child relationship to guide future research. In their moderating effect model, the caregivers’ relationships with their children affect the strength of the relations between the traumatic events and the children's symptomatic responses. Maternal depression may therefore affect this relationship (Colletti et al., 2009) and create a context of prolonged treatment-resistant PTSD in offspring (see also Pat-Horenczyk, Rabinowitz, Rice, & Tucker-Levin, 2009). We also test whether maternal PTSD symptoms moderate outcomes similar to those of maternal depression as there is evidence to suggest maternal PTSD symptoms are predictive of child outcomes in longitudinal research (Laor, Wolmer, Mayes, & Gershon, 1997). Child comorbid depression and separation anxiety symptoms were also tested as moderators given the findings of Berman et al. (2000). Finally, we explored age, gender, and minority status, but did not expect effects based on past research. Hypotheses were tested via hierarchical linear modeling (HLM; Bryk and Raudenbush, 1987 and Bryk and Raudenbush, 1992). HLM analyses are ideally suited for formally testing moderators of treatment outcomes (differential symptom change) across pretreatment to follow up where sharp declines are expected from pre-to post treatment followed by smaller decreases or leveling off from post treatment to follow up (i.e., a curvilinear trajectory). HLM provides an efficient approach to modeling complex trends in individual outcome over time (as well as the effects of between subjects variables), including the curvilinear relations expected (Tate & Hokanson, 1993) and so would provide a methodological advance to the extant literature by modeling the expected growth curves and formally testing maternal and child characteristics as moderators of these curves. HLM has the additional advantage for use with missing data common in treatment studies that are problematic for conventional repeated measures techniques (ANOVA's) for the participants across all three measurement points (pre, post, six-month follow-up).

نتیجه گیری انگلیسی

3. Results Level 1 HLM analyses tested linear and curvilinear trends in the individual growth curves using restricted maximum likelihood estimation with robust standard errors. The results of the HLM analysis of the overall within subject change curves indicated significant linear [t(34) = −4.01, p < .05] and quadratic [t(34) = 2.73, p < .05] components [overall X2(55) = 104.57, p < .001] for PTSD symptoms (and SAD symptoms see below). The significant curvilinear pattern is consistent with the anticipated large declines from pre-to post treatment followed by smaller decreases from post-treatment to follow up. Level 2 analyses indicated that there were no significant effects of age, minority status, or gender on the linear or curvilinear effects. The results of the HLM analyses on the effect of maternal depression are presented in Table 1 and depicted visually in Fig. 1. As shown in Table 1, high maternal depression was associated with greater initial PTSD symptoms (p < .05). Also, results indicated a significant effect of maternal depression (p < .05) for the quadratic trend, indicating that there was a significant difference in the individual change curves in PTSD symptoms depending on level of maternal depression. As can be seen from Fig. 1 the trend shows a steeper initial decrease followed by a return to increased PTSD symptoms for children with high (highest quartile in the sample) maternal depression. The effects of maternal depression on change in ADHD, ODD or child depression outcomes were not significant; however, separation anxiety was significant applying a one tailed test [intercept t(54) = 1.90, p < .05 one tailed; and quadratic t(33) = 1.88, p < .05 one tailed; model X2(54) = 135.72, p < .001]. As can be seen from Fig. 1 the trend shows higher initial SAD symptoms, then an initial decrease followed by a return to increased SAD symptoms for children with high maternal depression. Table 1. HLM estimation of the influence of maternal depression on treatment maintenance of PTSD symptoms. Fixed effect Coefficient Standard error t df p Intercept 14.50 1.60 9.08 53 <.001 Maternal depression 1.25 0.49 2.57 53 .013 For linear slope Intercept −8.81 1.93 −4.56 32 <.001 Maternal depression −1.36 0.59 −2.32 32 .027 For curvilinear slope Intercept 1.59 0.47 3.41 32 .002 Maternal depression 0.38 0.14 2.72 32 .011 Note: Model random effects X2(53) = 101.03, p < .001. Table options Growth curves depicting the influence of maternal depression on treatment ... Fig. 1. Growth curves depicting the influence of maternal depression on treatment maintenance of child PTSD and SAD symptoms. Figure options The effect of maternal PTSD symptoms on change in child PTSD symptoms were not significant [linear and quadratic p's > .1; the relation of maternal PTSD symptoms on Child PTSD symptoms intercept was significant applying a one tailed test; intercept t(54) = 1.74, p < .05 one tailed]. The effect maternal PTSD on change in child separation anxiety was significant [intercept t(54) = 3.67, p < .01; and quadratic t(32) = 3.04, p < .01; model X2(54) = 177.93, p < .001]. As can be seen from Fig. 2 the trend shows higher initial SAD symptoms, then an initial decrease followed by a return to increased SAD symptoms for children with high maternal PTSD. When maternal depression was also included in the model the effect of maternal PTSD on child SAD symptom trajectories remained significant [quadratic t(30) = 2.51, p < .05] while the effect of maternal depression was not evident [quadratic t(30) = 0.43, p > .1; overall model X2(53) = 182.10, p < .001]. Maternal PTSD symptoms did not have a statistically significant effect on any other child outcomes (all p's greater than .1). Growth curves depicting the influence of maternal PTSD on treatment maintenance ... Fig. 2. Growth curves depicting the influence of maternal PTSD on treatment maintenance of child SAD symptoms. Figure options Child SAD symptoms did show a significant effect on child PTSD symptom outcomes [intercept t(58) = 2.72, p < .01 two tailed; and quadratic t(36) = 2.22, p < .05 two tailed; model X2(58) = 100.00, p < .001]. However, when maternal depression was also included in the model the effect of child SAD on child PTSD symptoms trajectories was not evident [quadratic t(30) = 1.08, p > .1] while the effect of maternal depression remained significant [quadratic t(30) = 2.34, p < .05 two tailed; overall model X2(54) = 92.68, p < .001].

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