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Research Domain Criteria (RDoC) has posited a set of social dimensions that could be useful in identifying sources of individual variation in social impairments across neurodevelopmental disorders. The current investigation aimed to derive estimates of the RDoC social constructs from the Social Communication Questionnaire (SCQ) and examine whether RDoC social processes, as captured by the SCQ, are best represented by a dimensional, categorical, or hybrid model. Individual SCQ items from 4 databases were combined resulting in a total of 26,407 individuals ( M age  = 8.13 years, SD age  = 4.19; 69.1% male). The sample consisted of 60.0% of individuals with autism spectrum disorder (ASD), 6.8% with a range of neurodevelopmental disorders and 33.2% of siblings of individuals with ASD. Comparison of a range of factor solutions through the use of exploratory structural equation modeling and confirmatory factor analysis indicated that a 3-factor structure with separate attachment and affiliation, production of nonfacial and facial communication factors provided excellent fit to the data (comparative fit index = .989, Tucker-Lewis index = .984, root mean square error of approximation = .045). and robustness across clinical groups, age, sex, and verbal status. Comparison between the best-fitting factor analysis, latent class analysis, and factor mixture analysis solutions demonstrated that the RDoC social processes domain is best represented as dimensional. Our findings show promise for capturing some of the important RDoC social constructs using the SCQ but also highlight crucial areas for the development of new, dedicated dimensional measures.

Objective : To evaluate short forms of free self-report mania and depression scales, evaluating their reliability, content coverage, criterion validity, and diagnostic accuracy. Method : Youths age 11 to 18 years seeking outpatient mental health services at either an Academic medical clinic ( N = 427) or urban Community mental health center ( N = 313), completed the General Behavior Inventory (GBI) and other rating scales. Youths and caregivers completed semi-structured interviews to establish diagnoses and mood symptom severity, with GBI scores masked during diagnosis. Ten- and seven-item short forms, psychometric projections, and observed performance were tested first in the Academic sample and then externally cross-validated in the Community sample. Results : All short forms maintained high reliability (all alphas >.80 across both samples), high correlations with the full-length scales ( r .85 to.96), excellent convergent and discriminant validity with mood, behavior, and demographic criteria, and diagnostic accuracy undiminished compared to using the full-length scales. Ten-item scales showed advantages in terms of coverage; the 7 Up showed slightly weaker performance. Conclusions : Present analyses evaluated and externally cross-validated short forms that maintain high reliability and content coverage, and show strong criterion validity and diagnostic accuracy - even when used in an independent sample with very different demographics and referral patterns. The short forms appear useful in clinical applications including initial evaluation, as well as in research settings where they offer an inexpensive quantitative score. Short forms are available in more than two dozen languages. Future work should further evaluate sensitivity to treatment effects and cultural invariance.

To develop short forms of parent-rated mania and depression scales, evaluating their reliability, content coverage, criterion validity, and diagnostic accuracy. Caregivers completed the Parent General Behavior Inventory about their youth 5-18 years of age seeking outpatient mental health services at either an academic medical clinic ( n  = 617) or urban community mental health center ( n  = 530), along with other rating scales. Families also completed a semistructured Kiddie Schedule for Affective Disorders and Schizophrenia interview, with the rating scales masked during diagnosis. Ten-item short forms and projections of their psychometrics (vs. the full-length 46-item Depression and 28-item Hypomanic/Biphasic scales) were built in the academic sample and then externally cross-validated in the community sample. The mania and two depression short forms maintained high reliability (αs > .87 across both samples); high correlations with the full-length scales ( r s> .93); excellent convergent and discriminant validity with mood, behavior, and demographic criteria; and diagnostic accuracy undiminished compared to using the full-length scales. Present analyses developed and externally cross-validated 10-item short forms that maintain high reliability and content coverage and show strong criterion validity and diagnostic accuracy-even when used in an independent sample with markedly different demographics and referral patterns. The short forms appear useful in clinical applications, including screening and initial evaluation, as well as in research settings, where they offer an inexpensive quantitative score. Future work should further evaluate sensitivity to treatment effects. The short forms are available in more than a dozen translations.

In 2018, De Los Reyes and Langer expanded the scope of the Evidence Base Updates series to include reviews of psychological assessment techniques. In keeping with the goal of offering clear "take-home messages" about the evidence underlying the technique, experts have proposed a rubric for evaluating the reliability and validity support. Changes in the research environment and pressures in the peer review process, as well as a lack of familiarity with some statistical methods, have created a situation in which many findings that appear "excellent" in the rubric are likely to be "too good to be true," in the sense that they are unlikely to generalize to clinical settings or are unlikely to be reproduced in independent samples. We describe several common scenarios in which published results are often too good to be true, including internal consistency, interrater reliability, correlation, standardized mean differences, diagnostic accuracy, and global model fit statistics. Simple practices could go a long way toward improving design, reporting, and interpretation of findings. When effect sizes are in the "excellent" range for issues that have been challenging, scrutinize before celebrating. When benchmarks are available based on theory or meta-analyses, results that are moderately better than expected in the favorable direction (i.e., Cohen's q ≥ +.30) also invite critical appraisal and replication before application. If readers and reviewers pull for transparency and do not unduly penalize authors who provide it, then change in research quality will be faster and both generalizability and reproducibility are likely to benefit.

Diagnostic accuracy of the Diagnostic and Statistical Manual of Mental Disorders -oriented Child and Adolescent Symptom Inventory (CASI-4R) Psychotic Symptoms scale was tested using receiver operating characteristic analyses to identify clinically significant psychotic symptoms. Participants were new outpatients ( N  = 700), ages 6.0 to 12.9 years ( M  = 9.7, SD  = 1.8) at 9 child outpatient mental health clinics, who participated in the Longitudinal Assessment of Manic Symptoms (LAMS) Study baseline assessment. Because LAMS undersampled participants with low mania scores by design, present analyses weighted low scorers to produce unbiased estimates. Psychotic symptoms, operationally defined as a score of 3 or more for hallucinations or 4 or more for delusions based on the Schedule for Affective Disorders and Schizophrenia (K-SADS) psychosis items, occurred in 7% of youth. K-SADS diagnoses for those identified with psychotic symptoms above threshold included major depressive disorder, bipolar spectrum disorder, attention deficit/hyperactivity disorder, posttraumatic stress disorder, psychotic disorders, and autism spectrum disorder. The optimal psychosis screening cut score (maximizing sensitivity and specificity) was 2.75+ (corresponding diagnostic likelihood ratio [DiLR] = 4.29) for the parent version and 3.50+ (DiLR = 5.67) for the teacher version. The Area under the Curve for parent and teacher report was .83 and .74 (both p  < .001). Parent report performed significantly better than teacher report for identifying psychotic symptoms above threshold ( p  = .03). The CASI-4R Psychosis subscale (J) appears clinically useful for identifying psychotic symptoms in children because of its brevity and accuracy.

This study examined the diagnostic and clinical utility of the Child and Adolescent Symptom Inventory-4 R (CASI-4 R) Depressive and Dysthymia subscale for detecting mood disorders in youth (ages 6-12; M = 9.37) visiting outpatient mental health clinics. Secondary analyses (N = 700) utilized baseline data from the Longitudinal Assessment of Manic Symptoms study. Semistructured interviews with youth participants and their parents/caregivers determined psychiatric diagnoses. Caregivers and teachers completed the CASI-4 R. CASI-4 R depressive symptom severity and symptom count scores each predicted mood disorder diagnoses. Both caregiver scores (symptom severity and symptom count) of the CASI-4 R subscale significantly identified youth mood disorders (areas under the curve [AUCs] = .78-.79, ps < .001). The symptom severity version showed a small but significant advantage. Teacher symptom severity report did not significantly predict mood disorder diagnosis (AUC = .56, p > .05), whereas the teacher symptom count report corresponded to a small effect size (AUC = .61, p < .05). The CASI-4 R Depression scale showed strong incrememental validity even controlling for the other CASI-4 R scales. Caregiver subscale cutoff scores were calculated to assist in ruling in (diagnostic likelihood ratio [DLR] = 3.73) or ruling out (DLR = 0.18) presence of a mood disorder. The CASI-4 R Depressive subscale caregiver report can help identify youth mood disorders, and using DLRs may help improve diagnostic accuracy.

This study investigated the diagnostic and clinical utility of the parent-rated Screen for Child Anxiety Related Emotional Disorders (SCARED-P) for detecting youth anxiety disorders. Youth ages 6 to 12 years, 11 months were recruited from 9 outpatient mental health clinics (N = 707). Consensus diagnoses were based on semistructured interviews (Schedule for Affective Disorders and Schizophrenia for School-Age Children) with youth and caregivers; 31% were diagnosed with at least one anxiety disorder. Caregivers completed the SCARED-P to describe youth anxiety levels. SCARED-P scores were not considered during the consensus diagnoses. Areas under the curve (AUCs) from receiver operating characteristic analyses and diagnostic likelihood ratios (DLRs) quantified performance of the SCARED-P total score and subscale scores (generalized anxiety disorder and separation anxiety disorder). SCARED-P total scores had variable efficiency (AUCs = .69-.88), and Generalized Anxiety Disorder and Separation Anxiety subscale scores were excellent (AUCs = .86-.89) for identifying specific anxiety disorders. Optimal subscale cutoff scores were computed to help rule in (DLRs = 2.7-5.4) or rule out (DLRs < 1.0) anxiety disorders among youth. Results suggest that the Generalized Anxiety Disorder and Separation Anxiety SCARED-P subscales accurately identify their respective matched diagnoses. DLRs may aid clinicians in screening for youth anxiety disorders and improve accuracy of diagnosis.

Caregivers of psychiatrically impaired children experience considerable parenting stress. However, no research has evaluated parenting stress within the context of pediatric bipolar spectrum disorders (BPSD). Thus, the aim of this investigation was to identify predictors and moderators of stress among caregivers in the Longitudinal Assessment of Manic Symptoms study. Participants included 640 children and their caregivers in the Longitudinal Assessment of Manic Symptoms cohort. Children had a mean age of 9.4 ± 1.9 years (68% male, 23% BPSD); parents had a mean age of 36.5 ± 8.3 years (84% mothers). Children with BPSD had more service utilization, psychiatric diagnoses, mood and anxiety symptoms, and functional impairment but fewer disruptive behavior disorders. Caregivers of children with BPSD were more likely than caregivers of children without BPSD to have a partner, elevated depressive symptoms, antisocial tendencies, and parenting stress (Cohen's d = .49). For the whole sample, higher child IQ, mania, anxiety, disruptive behavior, and caregiver depression predicted increased parenting stress; maternal conduct disorder predicted lower stress. Child anxiety and disruptive behavior were associated with elevated caregiver stress only for non-BPSD children. Caregivers of children with BPSD experience significant burden and thus require specialized, family-focused interventions. As stress was also elevated, to a lesser degree, among depressed caregivers of children with higher IQ, mania, anxiety, and disruptive behavior, these families may need additional supports as well. Although parents with conduct/antisocial problems evidenced lower stress, these difficulties should be monitored. Thus, parenting stress should be evaluated and addressed in the treatment of childhood mental health problems, especially BPSD.