This review provides a meta-analysed male:female prevalence ratio of oppositional defiant disorder (ODD) during middle childhood in non-referred children. It also analyses sex differences in prevalence across cultures and over time. A systematic search for studies via the following sources was conducted: PsycInfo, Web of Knowledge, Medline Complete, Scopus, EMBASE, InfoRMIT, Psychological and Behavioural Sciences Collection, Cochrane Library, PubMed and ProQuest Health. The studies presented in two previous systematic reviews were also added to the search results. Inclusion/exclusion criteria were then applied and final studies were appraised for their methodological quality. Nineteen independent effect sizes met full inclusion criteria (aggregated sample N = 44,107). Overall, the prevalence of ODD was significantly higher in boys than girls (RR = 1.59, 95 % CI [1.36, 1.86], p < 0.001), with the male:female prevalence ratio found to be 1.59:1. Sex differences in prevalence were significant in Western (RR = 1.80, 95 % CI [1.55, 2.10], p < 0.001) but not non-Western cultures (RR = 1.08, 95 % CI [0.76-1.53], p > 0.05). Sex differences in prevalence were significant in studies published prior to and post the year 2000 (RR = 1.57, 95 % CI [1.22, 2.02], p < 0.001; RR = 1.64, 95 % CI [1.35, 2.00], p < 0.001), and were consistent between these two periods (Q, 1 = 0.36, p = > 0.05). The sex differences in ODD prevalence are discussed within the context of (i) predominant theories of sex differences in externalising behaviours, and (ii) departure from the sex-differences pattern found for other disruptive behavioural disorders.

Background: There is growing recognition that autistic females present with more diverse gender and sexual identities than their non-autistic counterparts. Likewise, autistic females are also at an increased risk of adverse sexual experiences. As higher rates of sexual victimisation are observed in individuals with diverse sexual identities in the broader population, rates of negative sexual experiences among autistic females remain unclear. This study aimed to investigate the representation of gender and sexual diversity within autistic females and examine their rates of regretted, and unwanted, sexual encounters among females with a transgender gender identity and nonheterosexual sexual orientation. Methods: Two hundred and ninety-five females completed the Sexual Behaviour Scale-III (SBS-III) online. Selfreported gender identity and sexual orientation were compared between 134 autistic (M age = 26.2 years, SD = 8.7) and 161 non-autistic females (M age = 22.0 years, SD = 4.6). Differences in the prevalence of negative sexual experiences were compared across diagnosis and each gender identity and sexual orientation label. Results: Autistic females were more likely to identify with a transgender gender identity (p < .05) and non-heterosexual sexual orientation (p < .007) compared to non-autistic females. Autistic homosexual females were more likely to have experienced a range of negative sexual experiences than autistic heterosexual females (OR ≥ 3.29; p < .01) and were more likely to have experienced unwanted sexual experiences than non-autistic females regardless of sexual orientation (OR ≥ 2.38; p < .05). There were no differences in rates of negative sexual experiences between autistic bisexual and both autistic heterosexual and non-autistic bisexual females. Non-autistic bisexual females (OR = 0.24; p = .018) presented with a reduced risk of regretted sexual experiences than non-autistic heterosexual peers. There were no differences in negative sexual experiences across gender identity in the autistic sample. Limitations: The use of fixed format response items may have restricted participants' abilities to provide rich responses pertaining to their sexual identities and nature of negative sexual experiences. The small number of participants who identified as transgender (n = 40) limits the reliability of results pertaining to sexual experiences across gender identity. Moreover, although multiple recruitment methods were used in this study, non-representative may bias estimates of prevalence rates. Thus, the data may not be representative of the broader population.

The aims of the current study were to (i) explore the potential bidirectional, prospective relationships between parenting and child ADHD, and (ii) explore whether these relationships differed on the basis of child gender. Data were obtained from waves 1 (children aged 4- to 5-years) to 5 (children aged 12- to 13-years) of the Longitudinal Study of Australian Child (LSAC) dataset (child cohort). In order to examine dimensions of both mothers' and fathers' parenting, a subsample of nuclear families with mothers, fathers and children present at all waves was extracted (final sample = 1932; sons = 981, daughters = 951). Child ADHD measures included the hyperactive-impulsive subscale of the strengths and difficulties questionnaire for symptoms, and parent-report question for diagnosis. Mothers and fathers completed scales on dimensions of Angry, Warm and Consistent Parenting. A cross-lagged panel model demonstrated (i) higher child ADHD symptoms at wave 1 led to a global increase in less-than-optimal parenting at wave 2, and (ii) child ADHD symptoms and Angry Parenting shared a prospective, bi-directional relationship (whereby increases in one predicted increases in the other over time) during earlier years of development. Latent growth curve models demonstrated that increases in Angry Parenting across time were significantly predicted by increases in child ADHD symptoms. A logistic regression demonstrated that both mothers' and fathers' Angry Parenting at wave 1 significantly predicted an ADHD diagnosis in children at wave 3. No predictive relationships differed between child genders; thus, it appears these prospective pathways are similar for both sons and daughters.

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