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Trends in Psychiatry and Psychotherapy

Print version ISSN 2237-6089On-line version ISSN 2238-0019

Trends Psychiatry Psychother. vol.38 no.1 Porto Alegre Jan./Mar. 2016  Epub Mar 18, 2016

https://doi.org/10.1590/2237-6089-2015-0036 

Original Articles

Measuring child maltreatment using multi-informant survey data: a higher-order confirmatory factor analysis

Dados de levantamento com múltiplos informantes para a mensuração de maus-tratos na infância: uma análise fatorial confirmatória de segunda ordem

Giovanni A. Salum1  2  3 

Diogo Araújo DeSousa1  3 

Gisele Gus Manfro2  3 

Pedro Mario Pan2  4 

Ary Gadelha2  4 

Elisa Brietzke2  4 

Eurípedes Constantino Miguel2  5 

Jair J. Mari2  4 

Maria Conceição do Rosário2  4 

Rodrigo Grassi-Oliveira2  6 

1Seção de Afeto Negativo e Processos Sociais, Hospital de Clínicas de Porto Alegre (HCPA), Porto Alegre, RS, Brazil

2Instituto Nacional de Psiquiatria do Desenvolvimento para Crianças e Adolescentes (INPD), São Paulo, SP, Brazil

3Universidade Federal do Rio Grande do Sul (UFRGS), Porto Alegre, RS, Brazil

4Universidade Federal de São Paulo (UNIFESP), São Paulo, SP, Brazil

5Universidade de São Paulo (USP), São Paulo, SP, Brazil

6Pontifícia Universidade Católica do Rio Grande do Sul (PUCRS), Porto Alegre, RS, Brazil


ABSTRACT

Objective

To investigate the validity and reliability of a multi-informant approach to measuring child maltreatment (CM) comprising seven questions assessing CM administered to children and their parents in a large community sample.

Methods

Our sample comprised 2,512 children aged 6 to 12 years and their parents. Child maltreatment (CM) was assessed with three questions answered by the children and four answered by their parents, covering physical abuse, physical neglect, emotional abuse and sexual abuse. Confirmatory factor analysis was used to compare the fit indices of different models. Convergent and divergent validity were tested using parent-report and teacher-report scores on the Strengths and Difficulties Questionnaire. Discriminant validity was investigated using the Development and Well-Being Assessment to divide subjects into five diagnostic groups: typically developing controls (n = 1,880), fear disorders (n = 108), distress disorders (n = 76), attention deficit hyperactivity disorder (n = 143) and oppositional defiant disorder/conduct disorder (n = 56).

Results

A higher-order model with one higher-order factor (child maltreatment) encompassing two lower-order factors (child report and parent report) exhibited the best fit to the data and this model's reliability results were acceptable. As expected, child maltreatment was positively associated with measures of psychopathology and negatively associated with prosocial measures. All diagnostic category groups had higher levels of overall child maltreatment than typically developing children.

Conclusions

We found evidence for the validity and reliability of this brief measure of child maltreatment using data from a large survey combining information from parents and their children.

Key words: Maltreatment; adversity; child; cohort; early life stress

RESUMO

Objetivo

Investigar a validade e confiabilidade de uma abordagem de múltiplos informantes para a mensuração de maus-tratos na infância, composta por sete questões avaliando maus-tratos na infância respondidas pelas crianças e seus pais em uma ampla amostra comunitária.

Métodos

A amostra foi composta por 2.512 crianças com idades entre 6 e 12 anos e seus pais. Maus-tratos na infância foram avaliados com três questões respondidas pelas crianças e quatro respondidas pelos seus pais, investigando violência física, negligência física, violência emocional e violência sexual. Análises fatoriais confirmatórias foram utilizadas para comparar os índices de ajuste de diferentes modelos. Validade convergente e divergente foi testada utilizando escores de relato parental e de relato dos professores no Strengths and Difficulties Questionnaire. Validade discriminante foi investigada utilizando a entrevista Development and Well-Being Assessment para dividir os participantes em cinco grupos diagnósticos: controles com desenvolvimento típico (n = 1.880), transtornos do medo (n = 108), transtornos do estresse (n = 76), transtorno de déficit de atenção-hiperatividade (n = 143) e transtorno opositivo-desafiador/conduta (n = 56).

Resultados

Um modelo de segunda ordem com um fator de segunda ordem (maus-tratos na infância) englobando dois fatores de primeira ordem (relato da criança e relato parental) demonstrou o melhor ajuste aos dados, e os resultados de confiabilidade desse modelo foram aceitáveis. Como esperado, maus-tratos na infância estiveram positivamente associados a medidas de psicopatologia e negativamente associados a medidas pró-sociais. Todos os grupos de categorias diagnósticas tiveram níveis mais altos de maus-tratos na infância do que as crianças com desenvolvimento típico.

Conclusões

Foram encontradas evidências de validade e confiabilidade dessa medida breve de maus-tratos na infância utilizando dados de um grande levantamento combinando o relato de pais e seus filhos.

Palavras-Chave: Maus-tratos; adversidade; crianças; coorte; estresse precoce

Introduction

Child maltreatment (CM) is a strong risk factor for many of the leading causes of death, disease, and disability.1-3 Child maltreatment involves a range of harmful behaviors that adults present towards children, including emotional, physical and sexual abuse, as well as emotional and physical neglect. Previous research has consistently associated CM with increased risk of poor physical health in adulthood4 and lifetime psychopathology.5,6

The conceptual and operational adequacy of risk assessment tools is debatable, with no definitive "gold" standard. Specifically, two important questions emerge from assessment of child maltreatment using survey data. First, the validity and reliability of short measures to assess a child maltreatment latent construct have rarely been examined. Second, integrating data from multiple informants into a single measure has been a challenge to researchers interested in a single estimate of the latent construct.

Here we report on data from the High Risk Cohort Study for Psychiatric Disorders (HRC Study),7 a Brazilian large community survey. We investigated the validity and reliability of a measure of child maltreatment comprising seven questions, three answered by the children and four answered by their parents. We also used confirmatory factor analysis to integrate information from multiple informants. Convergent and divergent validity were evaluated using measures of psychopathology symptoms and pro-sociality respectively. Groups with different psychiatric diagnoses were used to demonstrate discriminant validity.

Methods

Participants

The sample is part of a large, school-based, community study of children aged 6 to 12 years (at screening) from 57 schools in two Brazilian cities - Porto Alegre (n = 22) and São Paulo (n = 35). The research protocol was submitted to and approved by the Ethics Committees at the Universidade de São Paulo and the Universidade Federal do Rio Grande do Sul, Brazil, and written consent was obtained from parents of all participants, as well as verbal assent from all children before enrollment. Children who reported child maltreatment were invited to a clinical interview with a psychiatrist to investigate the level of exposure to CM and when appropriate, to be referred to child protection services. Child protection services are the institutions responsible for evaluating each case and, when a suspicion of CM is confirmed, for taking the appropriate legal measures. Additionally, all children with a positive diagnosis of a mental disorder were contacted for psychoeducation about the diagnosis and for referral to family health units for appropriate treatment.

During the screening phase, conducted on their school's registration day, 9,937 informants were interviewed using the Family History Survey (FHS).8 From this pool, we recruited two subgroups using a random (n = 958) and a high-risk (n = 1,514) group selection procedure, resulting in a total sample of 2,512 children.7 Subjects in the random stratum were selected using a simple randomization procedure based on school rolls, without replacement of non-available subjects. Selection for the high-risk stratum involved a risk-prioritization procedure, focused on individuals with a family history of a disorder and/or ongoing symptoms in one of five targeted domains (attention deficit hyperactivity disorder [ADHD], anxiety, obsessive-compulsive disorder [OCD], psychosis and learning disorders), as detected during screening. Subjects in this second, high-risk stratum were oversampled and, if not available, replaced by the next subject listed in the high-risk sampling frame. The details of the sample selection procedures can be found elsewhere.7 Of these 2,512 subjects, all parent reports on child maltreatment were available (94.9% answered by biological mothers and 5.1% answered by biological fathers). A total of 2,213 (88.1%) child reports on CM were also available.

Child maltreatment assessment

The questions about child maltreatment were selected to represent four categories of CM that have been distinguished in the literature: a) physical abuse (infliction of bodily injury by non-accidental means); b) neglect (failure to provide minimum care and/or lack of supervision); c) emotional maltreatment (pervasive and extreme thwarting of a child's basic emotional needs); and d) sexual abuse (sexual contact or attempted contact for purposes of sexual gratification or financial gain).9 Similar questions are frequently used in survey research10-12 and they are close to the constructs evaluated by other instruments that assess child maltreatment more comprehensively, such as the Childhood Trauma Questionnaire.13-16

Trained lay interviewers administered the research protocol to parents, using the following questions:

  • - Has [name of the child] ever been seriously beaten by an adult (including yourself) at home, hurting him/her or leaving bruises or marks?

  • - Has [name of the child] ever not had enough to eat or been forced to use dirty or torn clothes?

  • - Has [name of the child] ever been cursed with words like stupid, idiot, dumb or useless or been exposed to someone shouting or screaming?

  • - Has anyone ever done anything sexual with [name of the child] or threatened to hurt him/her if [name of the child] refused to do it?

The first three questions were also rephrased to make them apply to the children and administered by trained clinical psychologists, as follows:

  • - Have you ever been seriously beaten by an adult at home, hurting you or leaving bruises or marks?

  • - Have you ever not had enough to eat or been forced to use dirty or torn clothes?

  • - Have you ever been cursed with words like stupid, idiot, dumb or useless or been exposed to someone shouting or screaming?

Responses to these seven questions were rated on a 4-point scale: 0, never; 1, one or two times; 2, sometimes; 3, frequently. The forms used in the study are available on request.

Strengths and Difficulties Questionnaire (SDQ)

The SDQ is a measure of mental health problems in children that can be administered to their parents or teachers or to the children themselves.17-19 It comprises 20 items related to emotional symptoms, conduct problems, hyperactivity, and peer problems, rated on a 3-point scale, as follows: 0, not true; 1, somewhat true; 2, certainly true. Item scores were summed to create a total difficulty score ranging from 0 to 40. The SDQ also contains five items investigating prosocial behaviors. These questions are then followed by a single item assessing whether the respondent thinks that the child has a problem with "emotions, concentration, behavior, or being able to get along with other people" (response options: no problems, minor problems, definite problems, and severe problems). This last item is used to classify the impact caused by the psychiatric symptoms assessed. The Brazilian version of the SDQ was used in this study. This measure has been translated into Brazilian-Portuguese and has previously been used in large community investigations.20 Parent SDQ reports were available for all of the children in the sample (n = 2,512). Teacher SDQ reports were also available for a subset of 1,189 of the children. Some children had more than one teacher, in which case the teacher who was spending more time with the child was chosen to answer the SDQ.

Psychiatric diagnosis

Psychiatric diagnoses were established using the Development and Well-Being Assessment (DAWBA).21 The DAWBA is a structured interview administered by lay interviewers who also record verbatim responses of any reported problems. Verbatim responses and structured questions are then carefully evaluated by psychiatrists, who confirm or refute diagnoses. All questions are closely related to diagnostic criteria from the Diagnostic and Statistical Manual of Mental Disorders, 4th edition (DSM-IV), and focus on current problems causing significant distress or social impairment. The DAWBA has been translated into several languages, and for the present study we used the Brazilian-Portuguese version,22 administered to a biological parent who was legally responsible for the child. Administration was performed in accordance with previously reported procedures.21 Nine psychiatrists performed the rating procedures, all trained and supervised by a senior child psychiatrist.

For the purposes of this study we allocated each child to one of five non-overlapping groups: 1) typically developing controls (TDC; n = 1,880): subjects without any psychiatric disorder; 2) ADHD: subjects with any ADHD subtype (n = 143); 3) fear disorders: subjects with separation anxiety disorder, social anxiety disorder, specific phobia, or agoraphobia (n = 108); 4) distress disorders: subjects with generalized anxiety disorder, depression (major or not otherwise specified), or posttraumatic stress disorder (n = 76); or 5) oppositional defiant disorder or conduct disorder (ODD or CD; n = 56). All subjects with co-morbid conditions were excluded from these analyses. These diagnostic groups were chosen on the basis of evidence from twin studies23,24 and research on symptom structure.25-29

Data analysis

Since we aimed to combine information from child and parent reports and at the same time to fit a unidimensional measure of child maltreatment, we used confirmatory factor analysis (CFA) to test three theoretical models: a unidimensional model (all items loading into a single child maltreatment estimate); a bifactor model (all items loading into a general maltreatment estimate and residuals loading into a parent group factor and a child group factor); and a higher-order model (a higher-order factor of child maltreatment fully encompassing two lower-order factors - child and parent report). The small number of indicators precluded use of CFA to analyze multitrait-multimethod matrices.

The CFA models were fitted to polychoric correlations among items using the weighted least squares means and variance adjusted (WLSMV) estimator implemented in Mplus 7.0 software.30 Model fit was deemed adequate if the comparative fit index (CFI) and the Tucker-Lewis index (TLI) were ≥ 0.95 and the root square mean error of approximation (RSMEA) was < 0.06. Model fit was deemed acceptable if CFI and TLI were ≥ 0.90 and RMSEA was < 0.08.31,32

In Mplus, CFA can be used to investigate both factor loadings and thresholds. Factor loadings indicate how well the question reflects the underlying dimension, i.e., the relative contribution that each item makes to the latent trait. Threshold parameters reflect the standardized level of severity of the latent trait at which subsequent response options become more probable than the previous option (i.e. for choosing a response option of frequently or higher vs. sometimes or lower). Confirmatory factor analysis with categorical indicators is equivalent to item response theory (IRT) analyses of these parameters, with factor loadings being analogous to item discrimination parameters, and item thresholds being analogous to item difficulty parameters or item location parameters. Scale reliability was estimated from CFA results.33,34 Missing data on child reports were assumed to be distributed at random. The Mplus pairwise present method was used to estimate scores for subjects with missing information.

Pearson coefficients were calculated for correlations between the factor scores that emerged from CFA of the model that presented the best fit and the total and subscale scores of parent and teacher SDQ reports. The SDQ scores were used to investigate convergent and divergent validity. We hypothesized that the higher the level of child maltreatment report, the higher the number of psychiatric symptoms, and so such a finding would provide evidence of convergent validity. We also hypothesized that the lower the levels of maltreatment, the higher the number of prosocial behaviors, and so observation of this relationship would provide evidence of divergent validity. Discriminant validity was investigated using one-way analysis of variance (ANOVA) to compare the five groups divided according to their diagnostic categories in the DAWBA, using false discovery rate to control for multiple comparisons.

Results

The sample was 46.9% female (n = 1,177) and had a mean age of 10.6±1.46 years. Socioeconomic status was classified as: middle (n = 1,624; 64.6%), high (n = 738; 29.4%) and low/very low (n = 150; 6%). The children's mean parent-reported total SDQ difficulties score was 15.0±7.9 and their mean teacher-reported SDQ was 10.0±7.25.

Confirmatory factor analysis and reliability

A unidimensional model encompassing all seven items did not provide an acceptable fit to the data (χ2 = 254.971, degrees of freedom [df] = 14, p < 0.001; RMSEA = 0.083 (90% confidence interval [90%CI] 0.074-0.092); CFI = 0.758; TLI = 0.637). A bifactor model with one general factor encompassing all items and two group factors (parent and child reports) did exhibit an adequate fit (χ2 = 26.147, df = 7, p = 0.0005; RMSEA = 0.033 (90%CI 0.020-0.047); CFI = 0.981; TLI = 0.942). However, inspection of the factor loadings revealed that the general factor only captured the variance of the parent report items. Therefore, all child items only loaded onto the child group factor, limiting the utility of the general factor and integration of information from both informants. The higher-order model with two lower-order factors (parent report and child report) and a higher-order factor (child maltreatment) presented the best fit to the data out of the three models tested (χ2 = 29.9, df = 13, p = 0.0047; RMSEA = 0.023 (90%CI 0.012-0.034); CFI = 0.983; TLI = 0.972), and the two-factor correlated models also exhibited appropriateness (same fit indices). Therefore, subsequent analyses were only performed for the higher-order model.

Working with this model, inspection of the factor loadings revealed that all factor loadings were above 0.40 (highest: child physical abuse report λ = 0.754; lowest: parent physical neglect report λ = 0.596). Inspection of item thresholds revealed that, as expected, the levels of child maltreatment required for endorsement of the questions followed the following ascending order: emotional abuse questions in both parent and child reports, physical abuse in both reports, physical neglect in both reports and, finally, sexual abuse in parent report (Table 1 and Figure 1).The model-based reliability computed from the model was 0.80 for the higher-order factor, 0.83 for the parent factor and 0.87 for the child factor (Table 2).

Figure 1 - Graphical representation of the higher-order child maltreatment model.  

Table 1 - Confirmatory factor analysis factor loadings and thresholds 

Estimate SE Est/SE p-value Category thresholds
Once or twice or higher Sometimes or higher Frequently or higher
Parent
Physical abuse 0.751 0.046 16.459 < 0.001 1.051 1.882 2.689
Physical neglect 0.438 0.044 9.927 < 0.001 1.284 1.889 2.564
Emotional abuse 0.606 0.042 14.383 < 0.001 0.143 0.622 1.571
Sexual abuse 0.523 0.074 7.058 < 0.001 1.992 2.770 3.156
Child
Physical abuse 0.754 0.042 18.098 < 0.001 1.035 1.542 2.196
Physical neglect 0.596 0.046 12.885 < 0.001 1.545 2.046 2.729
Emotional abuse 0.714 0.040 17.973 < 0.001 0.728 1.204 1.851

Est/SE = estimate divided by standard error; SE = standard error.

Table 2 - Schmid and Leiman transformation of the higher-order model estimates 

A B C D E F G H
Lower-order factor loading Higher-order factor loading Total Variance Explained by factors (A2) Item variance explained by higher-order factor (A*B)2 SQRT of the unexplained variance of lower-order factor √(1-B2) Residualized lower-order factor loading (A*E) Item variance explained by lower-order factor (F2) Item variance not explained by factors
Parent
Physical abuse 0.751 0.707 0.564 0.282 0.707 0.531 0.282 0.436
Physical neglect 0.438 0.707 0.192 0.096 0.707 0.310 0.096 0.808
Emotional abuse 0.606 0.707 0.367 0.184 0.707 0.429 0.184 0.633
Sexual abuse 0.523 0.707 0.274 0.137 0.707 0.370 0.137 0.726
Child
Physical abuse 0.754 0.504 0.569 0.144 0.864 0.651 0.424 0.431
Physical neglect 0.596 0.504 0.355 0.090 0.864 0.515 0.265 0.645
Emotional abuse 0.714 0.504 0.510 0.129 0.864 0.617 0.380 0.490

SQRT = square root.

Convergent and divergent validity

As expected, both parent and teacher SDQ total scores and their scores for the subscales assessing emotional, hyperactivity, behavioral and prosocial problems exhibited small to moderate positive correlations with total CM, parent CM and child CM scores (except for the correlation between emotional symptoms reported by teachers and child-report CM). We also observed small negative correlations between the prosocial SDQ score in both parent and teacher reports and the total CM, parent CM and child CM scores. It should be noted that the magnitude of the correlations is attenuated from parent to teacher reports, which may reflect informant effects (i.e., parents informed on both child maltreatment and psychiatric symptoms; whereas teachers informed only on psychiatric symptoms) (Table 3).

Table 3 - Pearson correlation between factor scores from the higher-order model of CM and SDQ scores for reports by parents and teachers 

SDQ reported by parents (n = 2,512) SDQ reported by teachers (n = 1,189)
Total CM Parent CM Child CM Total CM Parent CM Child CM
Convergent validity
Total difficulties 0.418* 0.434* 0.238* 0.187* 0.177* 0.146*
Emotional symptoms 0.303* 0.319* 0.162* 0.081* 0.084* 0.047
Conduct problems 0.384* 0.393* 0.231* 0.188* 0.174* 0.154*
Hyperactivity 0.318* 0.328* 0.185* 0.132* 0.123* 0.107*
Peer problems 0.257* 0.269* 0.142* 0.170* 0.159* 0.136*
Impact 0.298* 0.325* 0.132* 0.162* 0.151* 0.132*
Divergent validity
Prosocial -0.214* -0.219* -0.131* -0.091* -0.087* -0.068

CM = child maltreatment; SDQ = Strengths and Difficulties Questionnaire. * p < 0.01 level; † p < 0.05.

Discriminant validity

There were significant differences in CM scores between groups selected according to DAWBA results, for the combined score (F4,2258 = 33.63, p < 0.001, ω2 = 0.055), parent score (F4,2258 = 33.57, p < 0.001, ω2 = 0.054) and child score (F4,2258 = 14.57, p < 0.001, ω2 = 0.023). Overall CM levels were higher in all diagnostic category groups than for the typically developing children (except for child scores in the comparison of fear vs. TDC), with moderate to strong effect sizes (Cohen's d ranging from 0.30 to 1.0). Comparisons between different diagnostic groups revealed that CM levels were higher in the distress and ODD/CD groups than in the ADHD and fear groups for combined and parent scores (but not for child scores). Post-hoc comparisons are shown in Table 4 and Figure 2.

Figure 2 - Lower-order and higher-order factor scores for non-overlapping diagnostic groups. ADHD = attention deficit hyperactivity disorder; SE = standard error.  

Table 4 - Post-hoc tests comparing levels of child maltreatment between non-overlapping diagnostic groups 

Combined score Parent score Child score
Group Mean diff t ds p FDR Mean diff t ds p FDR Mean Diff t ds p FDR
TDC
Fear -0.131 t(116) = -2.471 0.29 0.0020 -0.270 t(115) = -2.712 0.33 0.011 -0.063 t(118) = -0.926 - 0.396
Distress -0.434 t(79) = -6.749 0.95 < 0.001 -0.780 t(79) = -6.795 0.95 < 0.001 -0.405 t(80) = -4.642 0.62 < 0.001
ADHD -0.222 t(161) = -5.230 0.49 < 0.001 -0.374 t(162) = -5.070 0.46 < 0.001 -0.247 t(156) = -3.604 0.37 0.002
ODD/CD -0.440 t(57) = -5.521 0.96 < 0.001 -0.804 t(57) = -5.402 0.98 < 0.001 -0.388 t(57) = -3.515 0.59 0.003
Fear
Distress -0.303 t(159) = -3.690 0.55 < 0.001 -0.510 t(165) = -3.406 0.51 0.002 -0.342 t(153) = -3.146 0.48 0.005
ADHD -0.090 t(218) = -1.362 - 0.194 -0.104 t(207) = -0.858 - 0.436 -0.184 t(245) = -1.954 - 0.086
ODD/CD -0.309 t(103) = -3.264 0.55 0.003 -0.534 t(104) = -3.012 0.51 0.005 -0.325 t(96) = -2.539 0.44 0.025
Distress
ADHD 0.213 t(138) = 2.813 0.41 0.009 0.406 t(135) = 3.033 0.45 0.005 0.157 t(162) = 1.443 - 0.216
ODD/CD -0.006 t(114) = -0.059 - 0.953 -0.024 t(111) = -0.127 - 0.899 0.017 t(112) = 0.120 - 0.904
ADHD
ODD/CD -0.219 t(86) = -2.454 0.42 0.020 -0.430 t(82) = -2.620 0.46 0.013 -0.140 t(99) = -1.095 - 0.345

ADHD = attention deficit hyperactivity disorder; CD = conduct disorder; ds = Cohen's effect size measure; FDR = false discovery rate; Mean diff = mean differences; ODD = oppositional defiant disorder; t = t statistics; TDC = typically developing controls.

Supplemental analysis

Table 5 lists the levels of exposure for each type of maltreatment in our sample, in order to provide a clearer report of the level of exposure to CM in the sample. According to both child and parent reports, the most frequent type of CM was emotional abuse. As expected, frequencies of CM were higher in the high-risk subset than in the randomly selected subset (Table 5).

Table 5 - Frequencies of exposure to child maltreatment (CM) in the sample 

Randomly selected Selected by high risk Total
Child report
Physical abuse
No 744 (87.5) 1,132 (83.4) 1,876 (85.0)
One or two times 54 (6.4) 142 (10.5) 196 (8.9)
Sometimes 42 (4.9) 63 (4.6) 105 (4.8)
Frequently 10 (1.2) 21 (1.5) 31 (1.4)
Physical neglect
No 801 (94.3) 1,270 (93.6) 2,071 (93.9)
One or two times 29 (3.4) 61 (4.5) 90 (4.1)
Sometimes 17 (2.0) 21 (1.5) 38 (1.7)
Frequently 2 (0.2) 5 (0.4) 7 (0.3)
Emotional abuse
No 671 (79.0) 1,025 (75.2) 1,696 (76.7)
One or two times 93 (11.0) 170 (12.5) 263 (11.9)
Sometimes 64 (7.5) 118 (8.7) 182 (8.2)
Frequently 21 (2.5) 50 (3.7) 71 (3.2)
Parent report
Physical abuse
No 850 (88.8) 1,290 (83.2) 2,140 (85.3)
One or two times 93 (9.7) 200 (12.9) 293 (11.7)
Sometimes 13 (1.4) 53 (3.4) 66 (2.6)
Frequently 1 (0.1) 8 (0.5) 9 (0.4)
Physical neglect
No 884 (92.3) 1,378 (88.7) 2,262 (90.0)
One or two times 55 (5.7) 121 (7.8) 176 (7.0)
Sometimes 16 (1.7) 45 (2.9) 61 (2.4)
Frequently 3 (0.3) 10 (0.6) 13 (0.5)
Sexual
No 938 (98.1) 1,505 (97.4) 2,443 (97.7)
One or two times 16 (1.7) 35 (2.3) 51 (2.0)
Sometimes 1 (0.1) 4 (0.3) 5 (0.2)
Frequently 1 (0.1) 1 (0.1) 2 (0.1)
Emotional abuse
No 602 (62.8) 796 (51.3) 1,398 (55.7)
One or two times 157 (16.4) 286 (18.4) 443 (17.6)
Sometimes 152 (15.9) 372 (24.0) 524 (20.9)
Frequently 47 (4.9) 99 (6.4) 146 (5.8)
Exposure classification according to CFA estimates
Parent report
Low level 874 (91.4) 1,329 (85.8) 2,203 (87.9)
High level 82 (8.6) 220 (14.2) 302 (12.1)
Child report
Low level 749 (88.2) 1,181 (87.1) 1,930 (87.5)
High level 100 (11.8) 175 (12.9) 275 (12.5)
Any report (OR rule)
Low level 691 (80.8) 1,031 (74.8) 1,722 (77.1)
High level 164 (19.2) 348 (25.2) 512 (22.9)

Data presented as n (%). CFA = confirmatory factor analysis; OR = odds ratio.

We also used the CFA results to generate a categorical classification of the children's level of exposure. The category thresholds from the CFA results represent the standardized level of exposure to CM at which subsequent response options become more probable than the previous one and these were used to define "high exposure" in each type of maltreatment event, with a value of 1.5 deemed as indicative of high exposure. High exposure in parents' reports was then defined as: physical abuse and physical neglect rated sometimes or frequently, sexual abuse rated rarely, sometimes or frequently, and emotional abuse rated frequently. High exposure in children's reports was defined as: physical abuse rated sometimes or frequently, physical neglect rated rarely, sometimes or frequently, and emotional abuse rated frequently. Based on these criteria, the prevalence of high exposure to CM for any type of trauma in our sample was 12.1% according to parent-report scores and 12.5% according to child-report scores (Table 5).

Discussion

The purpose of this study was to investigate the validity and reliability of a child maltreatment measure comprising seven questions, three answered by children and four answered by the parents, in a large community sample. We found that a higher-order model including CM as a higher-order factor and the informants (child or parent) as lower-order factors exhibited the best fit to the data. We also found, as expected, that higher child maltreatment scores were positively associated with higher psychopathology scores and negatively associated with scores for prosocial behavior.35 Furthermore, all levels of overall maltreatment were higher among children from diagnostic category groups than among typically developing children. The prevalence rates of high levels of exposure to CM estimated in this study were 12.1% according to parent-report scores and 12.5% according to child-report scores, which is above global estimates that suggest that 1 in 15 (around 7%) children are victims of maltreatment annually.36 Since there is a lack of standardized Brazilian statistics on the prevalence of CM in community-based samples it is hard to compare this finding to national data.37 Our results provide initial evidence of the validity of this brief measure for assessment of child maltreatment. Large-scale studies often have to balance the comprehensiveness of the assessment measures with the time needed for assessment, in order to both capture the phenomena at hand and maintain study feasibility. We have demonstrated that a very brief instrument with a unidimensional structure was able to measure CM reliably and to differentiate psychopathology groups. Therefore, this might offer an effective alternative for large surveys that aim to assess CM but do not have enough time to use longer assessment protocols for this specific construct. Consistent with these aims, the measure presented in this study is among the least time consuming measures available in the current literature38 and among the few that have been shown to be valid for subjects in low and middle-income countries.15,39

Another important characteristic of this measure is that we used higher-order confirmatory factor analysis to integrate multiple sources of information about a phenomenon as complex as child maltreatment. Agreement between parents and children on rates of child maltreatment has been shown to be low to moderate40,41 but both have been shown to predict health-related outcomes.41 Therefore, reliance on a single source could overlook valuable information,42 since parents and children often have different perspectives43 and both are likely to be valid.41,42 More importantly, when reports from multiple informants are available, they are often analyzed separately. Higher-order CFA provides an interesting framework for conceptualizing the contributions of both parents and children to the same CM latent trait.

Lastly, although our CM assessment items may have face validity, we did not conduct a more thorough investigation of content validity. Nonetheless, the convergent, divergent, and discriminant validity results support the measure's criterion validity. As part of this approach, the questionnaire was administered to different groups that were expected to have different levels of the latent trait being measured, in order to confirm whether the difference hypothesized was reflected in the measure's scores.44 In this study we found higher levels of overall child maltreatment within groups with mental disorders, particularly among distress and ODD/CD groups.

This study has certain limitations. First, convergent validity with a measure of psychopathology symptoms was tested, but no other measure of child maltreatment was used. However, this limitation is linked to the absence of a gold-standard for evaluation of CM. Second, this assessment does not enable investigation of the nature or duration of CM events. Nonetheless, it is still an interesting option to measure CM unidimensionally considering the short time needed and the lower complexity of the assessment. Lastly, given the small number of indicators, multitrait-multimethod approaches could not be applied. In spite of this, we used a higher-order CFA approach to integrate information from both parents and children into a single measure and into specific measures of child maltreatment.

The study also has some important strengths. This is one of the few studies attempting to integrate multi-informant information into a single measure and one of the few investigating the validity of instruments specifically developed for survey data using a large community sample of children and early adolescents from a middle-income country.

In summary, this brief measure of child maltreatment has proven to be a valid and reliable instrument for large-scale community studies that aim to assess levels of child maltreatment in the population.

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Financial support: Conselho Nacional de Desenvolvimento Científico e Tecnológico (CNPq), Coordenação de Aperfeiçoamento de Pessoal de Nível Superior (CAPES), Instituto Nacional de Psiquiatria do Desenvolvimento para Crianças e Adolescentes (INPD; grant no. 573974/2008-0), Fundação de Amparo à Pesquisa do Estado de São Paulo (FAPESP; grant no. 2008/57896-8), and Fundação de Amparo à Pesquisa do Estado do Rio Grande do Sul (FAPERGS).

Erratum

We hereby inform a mistake in the first name of author Elisa Brietzke, in the article entitled "Measuring child maltreatment using multi-informant survey data: a higher-order confirmatory factor analysis" (doi: http://dx.doi.org/10.1590/2237-6089-2015-0036), published in ahead of print mode and included in the present issue (volume 38, issue 1, pages 23-32). In the author byline, "Eliza" should read "Elisa."

Received: January 17, 2015; Accepted: September 17, 2015

Correspondence: Giovanni Abrahão Salum Hospital de Clínicas de Porto Alegre Rua Ramiro Barcelos, 2350, room 2202 90035-003 - Porto Alegre, RS - Brazil E-mail: gsalumjr@gmail.com

No conflicts of interest declared concerning the publication of this article.

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