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Investigating the validation of the Chinese Mandarin version of the Social Responsiveness Scale in a Mainland China child population
© The Author(s). 2017
Received: 2 February 2016
Accepted: 30 December 2016
Published: 6 February 2017
Researchers from several different countries have found the Social Responsiveness Scale (SRS) to have good psychometric properties. However, to our knowledge, no studies on this subject have been reported in Mainland China. In this study, we investigated the psychometric properties of the Chinese Mandarin version of the SRS when used in Mainland China.
The reliability and validity of the parent-report SRS in a sample of 749 children of 4- to 14-year-olds: 411 typically developing and 338 clinical participants (202 with autism spectrum disorder (ASD)) were examined.
Internal consistency for total scale (0.871–0.922), test–retest reliability (0.81–0.94), and convergent validity with the Autism Behavior Checklist (ABC) (0.302–0.647) were satisfactory. The SRS total score discriminated between the ASD and other developmental disorders. Receiver operating characteristic (ROC) analyses revealed that the SRS was predicted to accurately classify 69.2–97.2% of youth ASD. Exploratory factor analysis (EFA) supported a single-factor solution for the ASD subsample. Confirmatory factor analysis (CFA) did not confirm the theoretical construct of five factors model with inadequate fit in the ASD subsample.
Overall, our findings supported the reliability and validity of the parent-report SRS as one ASD screening instrument. In addition, we also suggest that the use of separate cut-offs for screening purposes (optimizing sensitivity) vs. clinical confirmation (optimizing specificity) should be considered.
The Diagnostic and Statistical Manual of Mental Disorders (DSM-IV)  defines Autism Spectrum Disorders (ASD) as a group of developmental disabilities characterized by impairments in social interaction and communication, and by restricted, repetitive, and stereotyped patterns of behavior. The most common categories include Autism, Asperger syndrome (AS), and Pervasive development disorder-not otherwise specified (PDD-NOS), all currently conceptualized to lie on a continuum of autism-specific traits. The above definition, which contains only one diagnosis of ASD with varying degrees of severity, has been used by the DSM-V .
The prevalence of ASD has been reported to be constantly increasing. A 2012 review of global prevalence estimates of ASD found a median of 62 cases per 10,000 people . The prevalence estimates are presently up to 1 in 68 children under 8 years of age in the USA . In China, there has been a lack of large-scale epidemiological investigations on ASD. Sun. et al.  performed a systematic review and meta-analysis of relevant studies (from 1987 to 2011) from Mainland China, Hong Kong and Taiwan. The results indicated the prevalence of childhood autism in mainland China was 11.8/10,000, while pooled prevalence of ASD in all three areas was 26.6/10,000, which is significantly lower than that reported by above mentioned studies. Based on assessing the research methodologies of different prevalence estimates studies, the authors concluded that there was a potential under-diagnosis and under-detection of ASD in mainland China, Hong Kong and Taiwan. Considering that early detection of ASD can lead to treatments and support which improve functioning and quality of life, there is an urgent need for an efficient screening or identifying tool for ASD to facilitate the diagnose and further intervention in China.
The Autism Diagnostic Interview-Revised (ADI-R)  and the Autism Diagnostic Observation Schedule (ADOS)  are considered to be the ‘gold standard’ in diagnostic evaluations for autism, particularly when combined with clinical judgment . However, the autism research and clinical communities today face a global imbalance in our knowledge of autism and corresponding disparities in access to autism screening, diagnosis, and treatment exhibit globally . Both ADI-R and ADOS are costly, require extensive training, and are lengthy to administer, which limits their feasibility in clinical settings , especially in low resource countries . Consequently, ADI-R and ADOS cannot be administered as a routine part of the ASD evaluations in the clinical settings in China, due the lack of resources available for related assessment, diagnosis and intervention, and as well as restricted cover range of medical insurance. As already mentioned, rapid detection of ASD permits early diagnosis and treatment, which in turn increases the prognosis reliability for the patient [11, 12]. Therefore, time and cost effective measures which can identify potential at-risk cases for further assessments are urgent for the purpose of clinical and research settings in China.
Due to their easy applications and low cost, the Childhood Autism Rating Scale (CARS)  and the Autism Behavior Checklist (ABC)  have been frequently used in China as part of the diagnostic process in research and in clinical practice. The CARS is used to observe and subjectively rate fifteen items, scored from one to four for various criteria, ranging from normal to severe. The ABC consists of 57 items which are a list of atypical behaviors characteristic of the pathology and it is designed for the triage of children suspected of having autism. However, both above-mentioned assessing instruments may exhibit some of the following problems. First, proportion of the items which are associated with the repetitive and stereotyped behaviors and interests is too large in the ABC; Second, descriptions of the items in both assessments are excessively general and lack of specific behavioral descriptions, which may be considered to be ambiguous, giving rise to different interpretations; Third, most of the items in both assessments are about descriptions of severe autistic symptoms and very little is related with normal behaviors, which, consequently, would be difficult to reflect the concept of spectrum in ASD which ranging from mild to severe.
Reliability and validity studies on the SRS version for 4–18 years old
Authors and year
Area and main findings
1. Constantino et al.  
PDD 271, Siblings of PDD 254, non-PDD clinical 52
Teacher/parent correlation: 0.72.
Correlations with ADI-R: 0.15–0.43(teacher rating), 0.58–0.39(parent rating).
Correlations with ADOS: 0.26–0.40(teacher rating), 0.31–0.36(parent rating).
ROC curve of the PDD vs. non-PDD clinical and TD combined: AUC 0.95, T-score cut-off 60 resulted sensitivity 0.75 and specificity 0.96(both a parent and a teacher rating), specificity 84%(parent only), and specificity 90%(teacher only).
2. Bölte et al.  
TD 838, clinical527 (ASD 160, ADHD 134, other 233)
Internal consistency: 0.91–0.97.
Test–retest reliability: 0.84–0.97.
Interrater reliability: 0.76 and 0.95.
Correlation with ADOS, ADI-R and SCQ: 0.35–0.58.
Discriminant validity: total score discriminates ASD from other clinical conditions.
ROC analysis (ASD vs. other clinical): AUC 0.83, total score 85 had sensitivity 0.73 and specificity 0.81
Factorial validity: One-factor solution for normative and clinical subsamples.
3. Murray MJ. et al.  
29 suspected ASD
Agreement between ADI-R: 89.7%, kappa of 0.51.
Correlation with CASD: 0.40
Correlation with ADI-R : non-significant
4. Bölte et al.  
ASD 148, non-ASD clinical 255, TD 77
Internal consistency: 0.96 (ASD), 0.94 (non-ASD clinical) and 0.91 (TD).
Correlations with the ADI-R, ADOS, SCQ and SCDC were: 0.31–0.45, 0.32–0.35, 0.50, and 0.49.
ROC analysis of ASD vs. TD: AUC 0.98, sensitivity 0. 80 and specificity 1.0 (total score 75); sensitivity 0.74 and specificity 1.0 (total score 85).
ROC analysis of ASD vs. non-ASD clinical: AUC 0.81, sensitivity 0. 80 and specificity 0.69 (total score 75); sensitivity 0.74 and specificity 0.79 (total score 85).
ROC analysis of ASD vs. ADHD: AUC 0.86, sensitivity 0. 80 and specificity 0.78 (total score 75); sensitivity 0.74 and specificity 0.83 (total score 85).
5. Aldridge FJ. et al.  
48 suspected ASD
Diagnostic Sensitivity: 91% (parent report), 84% (teacher report)
Diagnostic specificity: 8% (parent report), 41% (teacher report).
6. Schanding GT. et al.  
ASD 1663, siblings of ASD 1712
Correlation with SCQ, ADOS, and ADI-R: 0.73, 0.35- 0.38, 0.08 - 0.25 (teacher rating).
Correlation with SCQ, ADOS, and ADI-R: 0.59, 0.12 - 0.16, 0.25 - 0.39 (parent rating).
ROC analysis: AUC 0.935 (teacher rating) 0.988 (parent rating), total score 60 had sensitivity 0.694 and specificity 0.953 (teacher rating), total score 75 had sensitivity 0.800 and specificity 0.994 (parent rating).
7. Wigham S.et al.  
52with and 414 without special needs
Internal reliability: 0.92 (total scale), 0.47-0.83 (subscales).
Correlation with RBQ2 and SDQ: 0.445 and 0.704.
Discriminant validity: total score discriminated children with ‘special needs’ and the ‘no special needs’ group.
Principal components analysis: a single factor structure
8. Wang J. et al.  
TD 140, clinical 167 (ASD, ADHD and other).
Internal consistency of total scale: 0.85 (TD), 0.87 (ASD), 0.92–0.94 (other clinical).
Internal consistency of subscale scale: 0.40–0.71 (TD), 0.36–0.83 (ASD), 0.43–0.90 (other clinical).
ROC analysis: cut-off 85 showed AUC 0.88, sensitivity0.66, specificity0.89. Suggested optimal cut-off for screening 65 with sensitivity 0.94 and specificity 0.70; Suggested optimal cut-off for clinical classification 87 with sensitivity 0.66 and specificity 0.90.
9. Fombonne E. et al.  
ASD 200, TD 363
Internal consistency for parent rating: 0.97 (total scale), 0.73–0.93 (subscale).
Internal consistency for parent rating: 0.97 (total scale), 0.79–0.93 (subscale).
Parent-teacher correlations: 0.49 (total scale):0.22–0.50 (subscale).
ROC analysis: AUC 0.962, optimal cut-off was 60 presented sensitivity 92.5% and specificity 92.6% (parent rating).
ROC analysis: AUC0.960, optimal cut-off was 59 presented sensitivity 93.6% and specificity 84.3% (teacher rating).
ROC analysis: AUC 0.984, optimal cut-off was 61 presented sensitivity 97.9% and specificity 88.1% (average of parent and teacher scores).
ROC analysis: AUC0.970, optimal cut-off was 87 presented sensitivity 86.4% and specificity 94.0% (highest value of parent and teacher scores).
10. Gau F. et al.  
TD 1419, ASD 401
Factor analysis: exploratory factor analysis yielded a 4-factor structure which was validated by confirmatory factor analysis with an adequate fit after excluding five items with low correlation coefficients.
Test-retest reliability: 0.751–0.852.
Internal consistency: 0.944–0.947.
Correlations with SCQ: 0.609–0.865.
Discriminant validity: ASD significantly higher than TD on total scale and subscales.
11. Duku E. et al.  
Internal consistency: 0.93 (total scale), 0.60–0.85 (subscale).
Confirmatory factor analysis: did not fit well and were not unidimensional.
Rasch analyses: showed a 30-item subset met criteria of unidimensionality.
Correlations between 30-item subset and 65-item total raw score: 0.94.
(30-item subset) Correlations with CBCL, RBS-R: 0.65–0.68.
12. Pearl AM. et al.  
ASD 26; TD24
Mother-father reliability: 0.92 (total scale), 0.80–0.93 (subscales).
13. Cholemkery H. et al.  
High-functioned ASD 55, ODD/CD 55, TD 55
ROC analysis of ASD vs. TD: AUC1.0, cut-off 43 showed sensitivity 0.98 and specificity 0.95.
ROC analysis of ASD vs. ODD/CD: AUC 0.82, total score 80 showed sensitivity 0.76 and specificity 0.82.
Combination with three other parent-rated questionnaires improved validity to differentiate ASD and ODD/CD.
Correlations with SCQ, ADI-R, CBCL: 0.55, 0.33 and 0.78.
While there have been studies regarding the investigation of the utilities of Chinese Mandarin version of SRS (Chinese SRS) in Taiwan, none have been reported yet in Mainland China. Although Mainland China and Taiwan are both Chinese-speaking areas, they are considered to have cultural differences. Furthermore, Mainland China is the largest or broadest Chinese-speaking region; despite the shared language between the Mainland China and Taiwan, it is necessary to carry out separate investigations on the usefulness of Chinese SRS in Mainland China. Therefore, the aim of the present study was to examine the psychometric properties of the Chinese SRS when used in a sample from Mainland China.
Participants of our study included clinical group and typically developing (TD) group, children aged 4–14 years. The clinical study group was composed of ASD, Attention Deficit Hyperactivity Disorder (ADHD), and Mental Retardation (MR) subgroups which were referred for developmental evaluation at the Child Developmental & Behavioral Division of the Third Affiliated Hospital of Sun Yat-sen University in Guangzhou, China, from April 2012 to July 2013. This hospital is a large-scale medical center in Mainland China. It’s Child Developmental and Behavioral Division is well known in Mainland China for specializing in the assessment, diagnosis and intervention related services for developmental disorders and conditions. Parents of a total of 338 children in the clinical group were consented and participated in the present study. The ASD subgroup (n = 202), included 98 individuals with autism, 63 with AS and 41 with PDD-NOS. The ADHD subgroup (n = 73) consisted of three subtypes: predominantly inattentive, predominantly hyperactive-impulsive, and the combined. 63 individuals were included in the MR group. All clinical diagnoses were confirmed by two developmental and behavioral pediatricians with extensive clinical and research experience in the assessment and treatment of children and adolescents with such conditions. The diagnoses were established by integrating data from parental interviews, developmental history and medical records, with information provided by other Caregivers and teachers, and direct observation and interaction with the study participants after at least three assessment visits. All diagnoses fulfilled the corresponding criteria of DSM-IV.
The TD group consisted of 411 children aged 4–14 years, whose parents were consented and participated in the study. In December 2012, we randomly selected one local kindergarten and one local primary school to also participate in the study. Two classes from each grade level (grades small, middle and junior in kindergarten aged 4–6; grades 1–6 in primary school, aged 6–14) were randomly selected from each school. Following, 15 children from each selected kindergarten class (90 in total) and 30 to 35 children from each selected primary school class (400 in total) were randomly chosen. These children had not previously been reported having developmental or psychiatric conditions, which were determined by information provided by their teachers. 411 participants in total were included in the final research. The participation rate was 83.9%.
In the TD group, the majority of the fathers and mothers of the participants were college graduates (89.0 and 84.9%) and about ten percent or above were senior high school graduates (9.7 and 13.9%). In the clinical group, more than half of the fathers and mothers were college graduates (58.8 and 56.5%) and about one quarter were senior high school graduates (25.0 and 23.8%), respectively. In terms of economic status, about one quarter of the participating families were in good economic standing (28.2%) and one quarter, in middle to low economic standing (71.8%) in the clinical group, and 40.5 and 49.5% respectively in the TD group. In addition, most of the respondents in both TD group (75.3%) and in clinical group (81.8%) were mothers.
Social Responsiveness Scale (SRS)
The present study used the Chinese SRS version for children aged 4–18 years. The SRS  is a 65-item questionnaire. Each item is scored on a Likert scale ranging from 1 (not true) to 4 (almost always true). When completed, a total raw score (ranging from 0 to 195, with higher scores indicating increased social impairment) and five theoretical subscales scores (labeled social awareness, social cognition, social communication, social motivation, and autistic mannerisms) can be generated. SRS focuses on the child’s behavior during the past 6 months and can be completed in 15–20 min by a parent, a teacher, or another frequent Caregiver. The SRS can be used in the following areas: as an ASD screener, as an aid to clinical diagnosis, as a quantitative ASD trait measurement and as a measure to monitor the response to the intervention, because it is able to measure subtle changes in the severity of symptoms over time.
Autism Behavior Checklist (ABC)
In order to investigate the convergent validity of the SRS, Autism Behavior Checklist (ABC)  of Chinese version was used in the current study. ABC is one of the most commonly used ASD assessment instruments in Mainland China. Similar to the SRS, the ABC is an unstructured parent or Caregiver-reported questionnaire. The ABC addresses 57 atypical behaviors (scored 1 to 4) related to five areas: sensory behaviors, relating behaviors, body and object use behaviors, language behaviors, and social self-help behaviors. The psychometric properties of the ABC have been studied for some years, and it has been considered useful in the screening of the children suspected of having autism. The developer of this scale proposed the total raw score of 68 for the cut-off point . The sensitivity ranged from 0.38 to 0.58, and the specificity ranged from 0.76 to 0.97 on the cut-off point 68. A systematic review of Brazilian studies related to psychometric properties of assessment instruments for autism spectrum disorder found that all studies aiming to validate instruments showed evidence of validity and sensitivity, and specificity values above 0.90 were observed in the ABC . The data from a Mainland China children sample indicated that when 50 or 62 was used as the ABC cut-off point to screen autism from the normal people the sensitivity of this scale were 0.97 and 0.95 respectively and the specificity were both 1.00, and when cut-off point 50 or 62 was used to differentiate autism from mental retardation (MR) the sensitivity of ABC were 0.97 and 0.95 and the specificity were 0.85 and 0.90 respectively .
The parents of the participants of the clinical group (n = 338) completed the SRS, and the parents of the 82 participants from the ASD subgroup (n = 202) completed the ABC while in the waiting room of the Child Developmental and Behavioral Division for their first doctor-visit. Clinicians were blinded to the SRS scores and ABC scores of the children in the clinical study groups when making diagnoses.
The parents of the participants of the TD group (n = 411) completed the SRS at home and later returned them to their children’s teachers. Teachers at participating kindergarten sent the Caregivers of participants the questionnaire when they met the Caregivers of participants after the classes are over for that day. For the primary school sample, the questionnaire was delivered to the parents by the participants. The package included a description of the measuring purpose, an explanation on how to fill out the survey and the contact number for further inquiries regarding the first page of the questionnaire. The participation rate was 83.9%, that is, 411 respondents were included. We randomly selected 23 primary school participants (grades 1–4, aged 6–9, and 56.5% boys) from the TD group to fill out the same questionnaire again at a 2-week interval to examine test–retest reliability.
Data analyses were performed using SPSS17.0 and AMOS 17.0 software. Raw SRS scores were used for all analyses. One-way Analysis of Variance (ANOVA) was carried out to compare mean age, SRS scores and IQ scores between four study groups (TD, ASD, ADHD, and MR), and Student-Newman-Keuls test (SNK) was performed for multiple comparison. Chi-square test was used to compare the sex distribution between the four study groups. T test was used to compare SRS scores between study groups (male vs. female, preschool age vs. school age). Spearman’s correlations were conducted to examine the correlation between total Raw SRS scores and age. Reliability was estimated by internal consistency (Cronbach’s alpha coefficient) of each subscale, and the total scale in TD and ASD sample, as well as test–retest reliability of the five subscales, and the SRS total score in TD sample using intra-class correlation. Criterion-related validity was analyzed in the ASD sample by using Spearman’s correlations to examine the relationships between SRS and the score of the ABC. Discriminant validity of each domain between different groups was explored by using ANOVA. The ability of the SRS to predict the diagnostic category for each of the cutoffs was examined by the receiver operating characteristic (ROC) analysis, using the area under the curve (AUC). The construct validity of the scale was explored using exploratory factor analysis (EFA) and confirmatory factor analysis (CFA). EFA was performed using principal factor and oblique promax rotation, which is an appropriate method for potentially correlated factors. CFA was performed by using the Structural Equation Model (SEM), and the model was fit to the data using the maximum likelihood (ML) estimation.
Demographic and Wechsler IQ characteristics of the study groups
Selected demographic characteristics, and Wechsler IQ by study groups
Male: n (%)
Age (years): mean ± SD
7.43 ± 2.08a
6.37 ± 2.35b
8.41 ± 1.65c
7.66 ± 2.06a
VIQ: mean ± SD
83.60 ± 28.05 a
98.65 ± 15.77 b
59.96 ± 15.09 c
PIQ: mean ± SD
84.88 ± 23.83 a
92.72 ± 14.56 b
64.96 ± 14.15 c
FIQ: mean ± SD
82.66 ± 26.65 a
95.43 ± 14.57 b
58.36 ± 14.79 c
SRS total raw score means by gender and age
SRS total raw score means by gender and age
Mean ± SD
39.38 ± 16.90
36.53 ± 14.40
38.32 ± 15.46
37.91 ± 15.85
91.59 ± 22.77
94.58 ± 24.17
94.11 ± 22.56
90.03 ± 23.13
64.17 ± 19.94
65.60 ± 15.19
62.00 ± 14.93
64.47 ± 19.52
77.57 ± 19.32
75.48 ± 24.60
73.62 ± 18.95
77.72 ± 21.66
Correlations between SRS total raw score and age in various study groups
Test-retest reliability and internal consistency
Test–retest reliability and internal consistency of the Chinese SRS
Pearson’s correlations between the subscales of the Chinese SRS and ABC
Body and object use
Analyses of discriminant validity of SRS
7.03 ± 2.56a
11.21 ± 2.92b
9.79 ± 2.64c
10.27 ± 2.44c
9.23 ± 3.86a
17.93 ± 5.20b
13.58 ± 4.89c
16.73 ± 4.59d
11.70 ± 6.08a
32.05 ± 8.66b
19.88 ± 7.84c
25.03 ± 8.74d
5.53 ± 3.29a
13.53 ± 4.92b
10.15 ± 4.16c
12.46 ± 4.44d
4.49 ± 3.76a
17.22 ± 6.02b
10.97 ± 4.72c
12.38 ± 5.76d
37.98 ± 15.77a
91.95 ± 22.90b
64.37 ± 19.27c
76.87 ± 21.05d
The exploratory factor analysis (EFA) indicated a single underlying factor which accounted for 17.56% of the variance. Of the remaining factors, one accounted for 7.38% of the variance, and the other 18 factors with an eigenvalue of 1 or more, accounted for no more than 4% each, which is typical for a single dimension solution. 47 of the 65 items had factor loadings greater than 0.2 onto factor 1.
By using the data of the ASD group, the factor model was established on the basis of theoretical construct of five factors on the original scale. Parameter estimation was based on a robust assumption of maximum likelihood estimation on the structural equation model. Several model-fitting indices were considered in order to indicate good structural parameters: the Chi-Square (χ 2), the goodness of fit index (GFI), the adjusted goodness of fit index (AGFI), the non-normed fit index (NFI), the comparative fit index (CFI), and the root mean square error of approximation (RMSEA) which measures the discrepancy between the approximation and the population. Fit indices for the five-factor model of the Chinese SRS base on Confirmatory factor analysis (CFA) using the ASD sample were conducted, with results displaying Chi-square (4055.958, P < 0.001), χ 2/df (2.023), GFI (0.566), AGFI (0.536), NFI (0.334), CFI (0.488) and RMSEA (0.072). Good-fit was indicated by non-significant Chi-square (or χ 2/df less than 3), GFI, AGFI, NFI and CFI of more than 0.9 respectively, and RMSEA of less than 0.07 , thus it can be expected that this five-factor model fitting is unsatisfactory.
Cut-off score, sensitivity, specificity, AUC, FNR, FEP, PPV, NPV based on ROC curve analysis to discriminate ASD and TD control, and ASD and non-ASD clinical groups
ASD vs. TD
ASD vs. ADHD
ASD vs. MR
ASD vs. ADHD and MR combined
SRS total raw score means by gender and age
In the U.S normalization data , a strong gender effect was found, with males generally rated about 9 SRS Total score points higher than males. Consequently, the differences of the magnitude evidenced in the SRS scores by gender were considered as factors that must be accounted for in norms. In keeping with the U.S. findings, in the UK normalization data, there was significant gender differences with males scoring 4.30 points higher than females. Boys had a 4.30 points higher SRS total raw score than girls of the same age . However, in our study, the mean SRS total scores were 2.88 points higher in boys than in girls among TD group, whereas an opposite pattern was found in the ASD group (2.99 points higher in girls than in boys), but both were not significantly different (P > 0.05). These patterns were consistent with that found in the Mexico study  in which no significant main effect for gender was found with 3.40 points higher in boys than in girls among control group, whereas an opposite pattern was found (11.3 points higher in girls than in boys) among PDD participants. Similarly, mild gender differences in the normative sample were also reported in the German study , which found that the boys were 2.50 points higher than girls in mother ratings and 1.4 points higher than girls in father ratings for the SRS total scores. The author explained that the sex differences are reported here for the sake of establishing norms, but subsequent analyses on the instrument’s psychometric properties were not conducted separately for boys and girls, since the gender differences were relatively modest . Thus, it can be seen, that the magnitude of gender difference for the SRS total score may vary in different samples or different data sources. However, there seemed to be such a trend in all the studies that boys always scored higher than girls on the SRS Total score in the normative sample which is the opposite of what in the clinical sample with girls always scoring higher than boys on the SRS total score, despite of different significant levels. Our study, consistent with Germany  and Mexico  studies, found that the sex differences of SRS Total score were less pronounced than that in the US normative sample. In this regard, it could be particularly of importance that a substantial part of the U.S.-standardization sample consisted of twins . Research on autism in general and autism traits on the SRS has shown that autism scores in twins, especially males, could be higher than those in the general populations [35, 36].
Our study found no significant differences between preschool-aged and school-aged samples on the SRS total scores either in the TD group, or in any of the clinical subgroups. Furthermore, there was no evidence that would lead to consider a linear correlation with significant level between the SRS total raw score and age in the total sample. This was in line with the U.S. study  which found that all of the various age groups were within around 0.2 standard deviation (SD) of the overall group mean, and the correlation of age with the SRS total scores across the 1636 participants resulted in a non-significant coefficient (r = 0.02). Similarly, German study demonstrated  no noteworthy correlations between age and the SRS total scores in the normative or clinical sample (r = −0.06 and 0.00). These findings consistently suggested few age effects on the SRS total raw score in cross-sectional studies.
Tests-retest reliability and internal consistency
The current study found the SRS tests-retest reliability to be ideal, which replicated the previous findings [15–17, 19, 23], confirming the stability of ratings over time for the SRS. This stability means that large changes in the SRS can be useful for detecting intervention effects. In keeping with the data from the U.S. original , Germany [17, 18], the UK , Taiwan [23, 24], Mexico  and Canada , the internal consistency for the SRS total scale of the current study was found excellent, with alpha coefficient in the order of 0.90. However, in our study, two of the five subscales - social awareness and social cognition - were unsatisfactory, with Alpha coefficient lower than 0.70. In addition, we revealed a pattern that the alpha values on “social awareness” (0.277–0.428) were always the lowest, while those on “social communication” (0.726–0.819) were contrarily, the largest in the five subscales, independently of which group or sample was examined. This was consistent with the findings of the previous studies conducted in the UK , Mexico , Taiwan  and Canada . Fombonne et al.  have argued that a consistent tendency for alpha is lower for the Awareness subscale and higher for the Communication subscale, most probably reflecting differences in the number of items comprised in each subscale (8 for Awareness and 22 for Communication).
Quite a few previous studies have established the concurrent validity of the SRS with the so-called gold standard clinical ASD instruments, including ADI-R [10, 17, 18, 37–39] and ADOS [17, 18, 38, 40], and with other rapid screening instruments including SCQ [17, 18, 24, 38, 39], CASD , SCDC , RBQ2 , and AQ . The vast majority of these studies have shown moderate to high correlations between the SRS score and the above mentioned instruments’ scores. For example, the study conducted by Bölte et al.  revealed correlations with the ADI-R, ADOS, SCQ and SCDC were 0.31–0.45, 0.32–0.35, 0.50, and 0.49, respectively. Taiwan data  indicated correlations with SCQ ranging from 0.609 to 0.865. And the SRS U.S. original data  demonstrated the SRS total score correlated with the ADI-R algorithm scores with r = .0.52–0.79. In this current study, our data revealed that the SRS had an acceptable concurrent validity with the ABC. It can thus be said that the SRS has a preferable and extensive concurrent validation in general.
As expected, we observed the highest SRS total scores in children with ASD, followed by other clinical subgroups and the TD. These data were in keeping with previous studies which all revealed that the ASD group scored dramatically higher than the non-ASD clinical group. Therefore, our data confirmed the previous research findings that the SRS could be used to distinguish the ASD from non-ASD clinical samples. Also, in our current study, despite the fact that ADHD and MR groups scored lower than the ASD group, they still scored remarkably higher than the TD group, which was similar to the previous study findings. For example, in the U.S. standardization sample, the ADHD, mood disorder and other psychiatric disorders were shown to yield intermediate scores, and Taiwan  and Germany  data revealed similar results. The former revealed that while significantly lower than the average SRS scores in children with ASD, the mean SRS scores of children in the ADHD/developmental delay (DD), ADHD alone, and DD alone groups were still notably higher than those of typical controls. And the latter study showed ADHD, neurotic/emotional disorder, ADHD + CD, CD and other psychiatric disorders to have notably higher mean SRS scores than the TD group. Additionally, as indicated by the study conducted by Pine et al. , when scores on the SRS, SCQ and CCC were compared for youths with mood or anxiety disorders, participants with mood and anxiety disorders obtained significantly higher scores on ASD symptom scales. There are several possible explanations for this score pattern. First, screening instruments including SRS may over-identify children at risk of an ASD . Subsequent studies, which included the use of the SRS as a measure of ASD symptomatology, have raised further important considerations regarding the use of this tool in some clinical settings . Therefore, it is important not to over-interpret parent report data alone as indicating “missed diagnosis” . In the ASD assessment and diagnostic clinical setting, this type of “missed diagnosis” or “over identifying” could be avoided by establishing a diagnosis which integrates diverse information or data, including clinical judgment. Secondly, quite a few studies have suggested that varying degrees of ASD traits extend in the general population from healthy individuals to clinical group [29, 44, 45]. ASD may represent the upper extreme of a constellation of traits that are continuously distributed in the population . Hence, the distribution of the intermediate elevated SRS score in the non-ASD clinical sample supported the dimensional perspective of ASD traits. Finally, despite the diagnostic rules applied in ICD-10 and DSM-IV, which do not allow for a co-morbid diagnosis of ASD and ADHD, many research studies have documented the coexistence of ASD and ADHD diagnoses . For example, one recent study reported that 18% of kids with ADHD showed an autism trait profile compared to 0.87% of the controls . Another recent study indicated that nearly one third of children with ASD also showed clinically significant symptoms of ADHD . Consequently, our study replicated the previous research findings of substantial overlap of symptomatology between ASD and ADHD, and highlights the importance of specifically examining the co-existing autistic traits in children with ADHD for better characterization of the underlying physiopathology and treatment . On this occasion, the SRS can help to obtain a more comprehensive understanding of these individuals’ social skills deficits.
In our study, the goodness-of-fit indices from the CFA indicated a poor fit for the five-factor structure comprising all 65 items of the SRS, which was consistent with the findings of the Canadian study , in which the authors also found that the two other tested models, a 5-factor first-order model and a 5-factor second-order model, with the subscales as factors, did not fit well. However, a study from Taiwan  found that the CFA of the normative sample had revealed a 4-factor model to fit well, which was demonstrated primarily by the EFA after excluding five items with low correlation coefficients. Thus, the five theoretic dimensions of the SRS could not be confirmed by the existing studies. Nevertheless, it seems reasonable, because the clustering of the original five subscales was based on clinical experience and use of intervention strategies, rather than by a confirmation through factor analysis . As recommend by the developers, the five theoretical subscales should only be used for the purpose of clinical description, including detection of the intervention effects.
The EFA in the ASD sample of our present study indicated a single underlying factor which accounted for 17.56% of the variance, and all subsequent factors explained markedly less variance than the first. This result was consistent with previous studies that supported a single-factor solution with varying degree of variance in different samples, e.g. the U.S normative study yielded a single-factor structure in both the normative and clinical samples, with the first factor accounting for the variance up to 70% in school sample . In the German data , 34.9% of variance in the clinical sample, and 16.5% (father rating), 17.5% (mother rating) of variance in the normative sample were explained as variance by the first factor. In addition, the UK  normative sample had the first factor accounting for 19% of the variance, which was similar normative sample from Germany . With respect to the differences in magnitude of variance explaining for the one-factor structure, Bölte et al.  suggest that it may have occurred on the basis of differences in age of the subjects in the respective samples, and the fact that in the published American school samples, informants were teachers (rather than parents), who each provided ratings on more than one student (15 on average). Another possible reason may be the different methods applied in the EFA. Generally, it is reasonable to regard the aforementioned findings as supporting a one-factor structure, and the SRS yield an overall autism score that is consistent with the notion of a single spectrum. At the same time, this result implied the total score rather than the subscale score or individual subscales score combination should be applied when using SRS for assist making decision of ASD.
In addition, the Social Responsiveness Scale has been revised to the Social Responsiveness Scale-2 . In the new assessment, the former five factors have been revised to be identified as "treatment clusters." A two-factor structure (corresponding to social communication impairment and restricted, repetitive behavior) as elaborated in the updated Diagnostic and Statistical Manual of Mental Disorders (5th ed.; DSM-5) criteria for autism spectrum disorder exhibited acceptable model fit in confirmatory factor analysis . This implies that the scoring of broad autism traits in the SRS-2 may be helpful in diagnostic contexts where separate measurements of DSM-5 domains are desired. Therefore, future studies are worthy to use our present data from the SRS and revise the analysis to use the SRS-2 norms and factors.
In ROC analyses, in keeping with the results of data from Germany (AUC =0.98) , Mexico (AUC =0.962) , Taiwan (AUC =0.997) , US (AUC =0.988) , and Germany (AUC =1.0) , the current study showed the parent-rating SRS total score to be distinguished excellently between ASD and TD (AUC = 0.972). In clinical practice, the SRS is generally used to indicate children for further diagnostic evaluation, thus requiring high sensitivity. Our study shows that the total raw cut-off score of 56.5 with a sensitivity of 0.950 could serve this purpose very well. Moreover, the aim to identify as much ASD cases as possible will go at the expense of the specificity, i.e. a considerable proportion of non-ASD cases will also be identified and selected for further diagnostic assessment, with the accompanying costs and burden on the families. In our study, the total raw cut-off score of 56.5 with the specificity of 0.90 is also effective in correctly identifying children who do not need further ASD-specific diagnostic assessment.
We also applied the SRS approach for discriminate the ASD from the non-ASD clinical subgroups. The AUC was significantly lower, with 0.821 for ASD vs. ADHD and 0.761 for ASD vs. non-ASD clinical combined, respectively. The sensitivities were 0.748/0.691, and specificities were 0.767/0.748, respectively, for the ASD using 77.5 as the cut-off SRS score. This was in line with the previous studies in which ASD vs. ADHD (AUC =0.86 ~ 0.88) [17, 18, 23], ASD vs. ODD/CD (AUC =0.82) , ASD vs. ADHD and other non-ASD clinical combined (AUC =0.81 ~ 0.879) [15, 17, 18, 23] were compared. However, the present studies so far may be inappropriate for a solid clinical classification due to the insufficient sensitivity and specificity. Moreover, the use of separate cut-off score of the SRS for screening purposes (optimizing sensitivity) vs. clinical confirmation (optimizing specificity), are well worth considering, as discussed in the SRS Manual . Choosing a higher cut-off point may be preferable when it is important to further minimize the number of false positives, i.e. children with non-ASD who are incorrectly identified at risk for ASD. Thus, clinicians and researchers should be aware of the trade-off between maximizing the identification of children at risk versus minimizing the number of children targeted to receive further assessments, when selecting the cut-off that best serves their particular purpose or the population screened.
While the findings from this current study provide some guidance regarding the clinical utility of this screening instrument, there are several limitations that need to be acknowledged. First of all, our sample was from Guangzhou, so our results should not be generalized to the whole population in Mainland China. Further population-based studies are needed to clarify the utility of the SRS in more diverse samples. Secondly, the ASD diagnoses of our study were not confirmed using standardized assessments including ADI-R and ADOS, because these assessment instruments for the Chinese version had not been available for the utilization in Mainland China. This may have influenced the SRS score distribution of the ASD subgroup. Thus, it is possible that some of the discrepancies observed between the SRS score and the ASD diagnosis were due to variability in how children were assessed and diagnosed in the clinical setting . All the clinical diagnoses in our study were established by extensively- experienced developmental and behavioral pediatricians from a medical center well-known for its specializing in the services for these conditions. Therefore, this concern should not have had a significant impact on the study’s findings. However, further studies involving the ASD sample confirmed by gold standard instruments, including ADI-R and ADOS, should be warranted to further clarify the usefulness of the SRS. Thirdly, regarding the concurrent validity, only one ASD screening tool, i.e. the ABC, was used to examine the correlation with the SRS in our study. It may have been insufficient to demonstrate this validity. Thus, further studies are needed to investigate this type of validity involving diverse ASD screening tools and ASD diagnostic assessments, particularly the ADI-R and ADOS, which are viewed as the “gold standard” for diagnosing the ASD. Fourthly, our study is also limited by it’s lack of the inter-tester reliability measure. Respondents in our study were completely parents (for the most part, mothers), and subsequent analyses of the instrument’s psychometric properties were not conducted separately for mothers and fathers. Therefore, it may have had an influence on the SRS score results, given that the U.S. normative study  as shown a difference between maternal, paternal, and teacher rating. As in previous research, moderately high correlations were reported between parent and teacher SRS rating and between father and mother SRS rating. For example, high correlations have been reported in the validation U.S. studies [15, 40], with parent-teacher correlations in the range of 0.70 and over, and, the studies conducted by Bölte et al.  and Pearl et al. , both demonstrating excellent father-mother SRS rating correlations with r =0.76–0.95. However, the study by Fombonne et al.  reported only a mild to intermediate correlation between parent and teacher SRS rating, with r =0.22–0.50. Besides, it should be noted that the correlation between informants was much higher in the clinical sample as compared to the control group . As a result, further studies should be warranted to systematically investigate the SRS score distributions in different respondents, and discrepancies between different respondents, particularly in the teacher respondents. It is because once the children attend schools, including kindergarten and primary schools, the teachers play a very important role as observers in the neutral context. They are able to gather information from a multidisciplinary team work , which is necessary and helpful for an accurate assessment of SRS used, as we know, primarily to evaluate the individual’s reciprocal social behavior.
In summary, the current study extends our knowledge regarding the clinical utility of the Chinese version of the SRS in the sample from Mainland China. Internal consistency, test–retest reliability, convergent validity and discriminant validity of our data were satisfactory to good. This further confirms that the SRS is an excellent method for identifying ASD classification with a high sensitivity and specificity; however, when applied for distinguishing the ASD from the non-ASD clinical subgroup, the sensitivity and specificity were lower. The results of the exploratory factor analysis were consistent with those as reported for the SRS original in indicating a single-factor structure in clinical samples. Our findings support the SRS as a parent-report measure of quantitative autistic impairment in the Mainland China. But, the use of separate cut-offs for screening purposes (optimizing sensitivity) vs. clinical confirmation (optimizing specificity) should be considered.
The authors gratefully acknowledge all families and their children for their participation in the current study. The authors would also like to thank the JINAN University Kindergarten and The Primary School Attached to JINAN University for their involvement in this study. Finally, the authors thank Dr. Jia-Ling Li for her assistance in performing the data statistical analyses of this study. This study was supported by the National Program on Key Basic Research Project (973 Program) in China (2012CB517900).
Our study is a branch of the National Program on Key Basic Research Project (973 Program) in China (2012CB517900). The funding body provides research funding support.
Availability of data and material
All data generated or analysed during this study are included in this published article.
CQC carried out the study, and drafted the manuscript. YYL played an important role ain interpreting the results, and revised the manuscript critically. QRC participated in drafting the manuscript. KYC participated in the conception and design of the study. HZD and BYC both participated in the data analyses. XBZ approved the final version. All authors read and approved the final manuscript.
The authors declare that they have no competing interests.
Consent for publication
Ethics approval and consent to participate
This experiment was approved by the Second Xiangya Hospital of Central South University Ethics Committee (SXHCSU-2011-165).
Parents of a total of 749 children with 338 in the clinical group and 411 in the typically developing group were verbally consented and participated in the present study.
Open AccessThis article is distributed under the terms of the Creative Commons Attribution 4.0 International License (http://creativecommons.org/licenses/by/4.0/), which permits unrestricted use, distribution, and reproduction in any medium, provided you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons license, and indicate if changes were made. The Creative Commons Public Domain Dedication waiver (http://creativecommons.org/publicdomain/zero/1.0/) applies to the data made available in this article, unless otherwise stated.
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