Ryan J. Persram1*
Tracy K. Y. Wong1
Luis Francisco Vargas-Madriz1Chiaki Konishi1
Nicole S. J. Dryburgh2Melanie A. Dirks2Alexa Martin-Storey3Wendy Craig4
- 1Department of Educational and Counselling Psychology, McGill University, Montréal, QC, Canada
- 2Department of Psychology, McGill University, Montréal, QC, Canada
- 3Department of Psychoeducation, Université de Sherbrooke, Sherbrooke, QC, Canada
- 4Department of Psychology, Queen’s University, Kingston, ON, Canada
Teen dating violence (TDV) victimization is a traumatic experience that can have adverse consequences for adolescents. Current measures that assess TDV do not fully distinguish between psychological and relational forms of aggression, nor do they capture aggressive acts that are common within adolescent relationships. The purpose of this study was to evaluate the psychometric properties of the Teen Dating Aggression Measure (TeDAM) using a sample of 730 Canadian adolescents (M = 15.88 years, SD = 1.23). The measure is an expansion of the Conflict in Adolescent Dating Relationships Inventory and includes items that describe other forms of violence such as coercion and control, along with more traditional indicators of dating violence (e.g., sexual aggression). Factor analyses yielded three factors, namely psychological aggression, sexual and physical aggression, and relational aggression, which were correlated with more frequent cannabis and alcohol use as well as rape myth acceptance. These results provide initial support for the utility of the TeDAM for assessing TDV with adolescents.
Introduction
Adolescence represents a developmental period marked by increased interest and involvement in extrafamilial romantic relationships with same or other-gender partners (Collins et al., 2009; Furman and Collins, 2009). Although teen dating is typically characterized by affectionate and anticipated or actual sexual behaviors, violence, and aggression can also occur (Wolfe et al., 2001; Collins et al., 2009). This type of aggression and violence is commonly referred to as teen dating violence (TDV) and is a prevalent social problem. In a recent study using the Health-Behavior in School-Aged Children (HBSC) survey, Exner-Cortens et al. (2021) found that one in three Canadian teenagers had some experience with dating violence in the past year. In particular, adolescents reported experiencing psychological aggression the most (27.8%), followed by cyber aggression (17.5%) and physical aggression (11.8%) (Exner-Cortens et al., 2021). Moreover, national statistics indicate that 20% of police-reported incidences included some form of dating violence among 15–24-year-olds (Statistics Canada, 2018). Finally, youth victims of TDV are more likely to experience adverse outcomes such as increased depression and anxiety (Garthe et al., 2021), engage in more substance abuse and risky sexual behavior (Alleyne et al., 2011), and are at greater risk for future intimate partner violence (IPV) (Exner-Cortens et al., 2013). Despite being a public health concern, current measures of TDV are limited for various conceptual and methodological reasons. To address these limitations, the purpose of this study was to evaluate the psychometric properties of a more expansive measure that evaluates TDV victimization more broadly.
Teen dating violence is conceptually similar to IPV observed among adult populations (Espelage et al., 2020). For example, TDV incorporates actions and behaviors that are intended to hurt or manipulate a partner’s social relationships and can be manifested in different ways (Linder et al., 2002; Breiding et al., 2015; Centers for Disease Control and Prevention, 2020). Instruments that assess TDV typically measure three types: (a) physical, (b) sexual, and (c) psychological violence (Smith et al., 2015; Exner-Cortens et al., 2016a,b). Physical dating violence refers to a range of behaviors in which an individual experiences physical injury such as hitting and kicking (Breiding et al., 2015). Sexual dating violence refers to behaviors in which a partner forces or attempts to force the partner to engage in physical or non-physical sexual acts (Breiding et al., 2015). Psychological dating violence denotes behaviors meant to humiliate or control the partner (e.g., name calling, restricting access to friends) (Breiding et al., 2015). However, what is unique to TDV is that it can differ based on the types of aggressive behaviors and actions that often take place amongst adolescent peer groups that may not be particularly salient among adults.
In general, victimization resulting from TDV is linked to various negative outcomes. For example, experiencing physical or verbal TDV is associated with recent alcohol and marijuana use (e.g., Parker et al., 2016). Moreover, adolescents who have been exposed to sexual assault have differential perceptions of rape myth acceptance, which refers to a stigmatic set of beliefs that victims are at fault for their assault or exposure to dating violence (e.g., Edwards et al., 2011; Dworkin et al., 2017). Subscales of rape myth acceptance include rape denial, which refers to attitudes reflective of victim-blaming or not believing rape victims, and traditional gender expectations, which represent typical roles of men and women in relationships (Dworkin et al., 2017). In Dworkin et al. (2017), positive associations between the two rape myth acceptance subscales and each of depressed mood and alcohol use among a sample of adolescents were evident. More broadly, positive associations were observed between rape myth acceptance as an overall measure and sexual dating aggression (Reyes and Foshee, 2013). Thus, the consequences of being victimized by a romantic partner has an effect on the ways in which adolescents might cope with and perceive such experiences.
Currently, there are several measures that assess TDV, each of which evaluate different aspects of teen dating perpetration and victimization (see Exner-Cortens et al., 2016a,b). A comprehensive review by Exner-Cortens et al. (2016a,b) highlights dating violence behaviors and attitudes as distinct themes for measuring TDV. Despite the breadth of these measures, there are two main limitations to note among them. First, many of the measures are adapted from adult scales that do not fully capture the adolescent experience (e.g., Conflict Tactics Scale; see Straus, 1979; Cascardi et al., 1999). Although adult-based dating violence measures could be adapted for use with adolescents, the nature of adapting remains problematic. From a developmental perspective, adolescent and adult intimate relationships differ in important ways (Knox et al., 2009). For example, adolescents are less likely to live with and be economically bound to their partner (Knox et al., 2009). Moreover, adolescents are also more likely to disclose victimization experiences with peers than adults, who are more likely to seek help from professionals (Knox et al., 2009). Furthermore, adolescents are likely to remain in contact with the partner because they often go to the same school or even attend the same class (Knox et al., 2009). Due to these differences, adult-based dating violence measures might not adequately capture the uniqueness of TDV. For example, including items that capture economic threats (e.g., removal of economic support) or failing to assess relational aggression (e.g., spreading rumors to friends) would not adequately capture adolescent developmental. As such, we argue that they do not fully capture the everyday aggressive acts that might be more common to the adolescent dating experience. This is especially the case for relationally and psychologically aggressive acts, as they are common during adolescence and occur in both dating and peer relationships (e.g., Linder et al., 2002; Ellis et al., 2009).
In adolescence, relationally and psychologically aggressive acts are common among teen dating partners relative to physical aggression (e.g., Morelli et al., 2018; Dosil et al., 2020; Asghari et al., 2021). In addition, psychological aggression appears to occur more frequently than relational aggression in the context of adolescent romantic relationships relative to those between adults (Morelli et al., 2018; Dosil et al., 2020). Similar to the aforementioned TDV experiences, adolescent victimization based on psychological or relational acts are associated with greater psychological distress in romantic relationships (Jouriles et al., 2009; Goncy et al., 2017), increased emotional and behavioral problems (e.g., Leadbeater et al., 2008), and alcohol use (Schad et al., 2008). As such, the inclusion of aggressive acts that adolescents commonly see in their romantic partners beyond what has been developed for adults is necessary.
Second, adolescent-based measures of TDV tend to have poor psychometric properties. For example, the Conflict in Adolescent Dating Relationships Inventory (CADRI) is a widely used instrument to measure teen dating perpetration and victimization and has been validated in many countries, including Canada, the United States, Spain, Mexico, among others (Wolfe et al., 2001; Smith et al., 2015; Exner-Cortens et al., 2016a,b). In terms of its factor structure, the CADRI includes five first-order factors, including threatening behavior, physical abuse, relational aggression, verbal emotional abuse, and sexual abuse, each of load onto a second-order latent factor called abuse. Moreover, internal consistency and test-retest reliability were adequate across adolescent sex and grade (>0.70) for verbal/emotional and physical abuse, but weaker for threatening behaviors (0.54–0.73), relational aggression (0.16–0.69), and sexual abuse (0.36–0.59) (Wolfe et al., 2001). Subsequent validation studies offered only partial psychometric evidence for the CADRI. For example, Fernández-Fuertes et al. (2006) assessed the five-factor model for both TDV perpetration and victimization with Spanish adolescents using exploratory factor analysis (EFA) instead of confirmatory factor analysis (CFA). Hokoda et al. (2006) only considered the reliability of CADRI for both TDV perpetration and victimization with Mexican youth. Furthermore, although the short form of CADRI (CADRI-S) has demonstrated validity and reliability among general and high-risk adolescents, it has lower sensitivity compared with the full CADRI (Fernández-González et al., 2012). Importantly, the CADRI-S was assessed only from the perpetuator’s perspective (Fernández-González et al., 2012). Thus, the extent to which CADRI or CADRI-S adequately measures TDV victimization experiences remains unclear.
The Measure of Adolescent Relationship Harassment and Abuse (MARSHA) is a recent and comprehensive instrument that aims to evaluate different aspects of TDV perpetration (i.e., social control, physical abuse, sexual abuse, isolation, cyber control, intimidation) and victimization (i.e., privacy control, social control, physical abuse, sexual abuse, and intimidation (Rothman et al., 2020, 2021). This measure was initially developed from focus groups and interviews with a group of adolescents and young adults (11–20 years old, Mage = 16.4) (Rothman et al., 2020), and its reliability and validity were evaluated with a culturally diverse sample (11–20 years old) that has a mean age of 18 (Rothman et al., 2021). Given that the validation group consisted mainly of older adolescents and young adults, the extent to which MARSHA adequately captures TDV victimization experiences during the period of adolescence is inconclusive.
Previous reviews have addressed several gaps in extant TDV measurements (Smith et al., 2015; Exner-Cortens, 2018). For example, items that measure sexual violence are often neglected or limited, possibly because of pressure from schools to avoid sexual related topics (Smith et al., 2015; Exner-Cortens, 2018). Moreover, psychological aggression (e.g., insulting) is often measured in a way that parallels physical aggression, which limits understanding on the nuances that distinguish the two constructs (Follingstad, 2007). To address these gaps, this study validated a comprehensive TDV victimization measure that was extended from the CADRI measure. This measure considers not only fundamental TDV constructs (i.e., physical abuse, psychological abuse, and sexual abuse), but also those that have not been adequately evaluated, such as relational forms of violence and aggression. The validation of the new measure was conducted in Canada, where TDV remains an alarming significant public health problem among adolescents (Shaffer et al., 2021).
The present study had three main objectives. First, we sought to extend the CADRI measure to include typical everyday actions and behaviors that could be experienced by adolescents who have been in a romantic relationship. Our second objective was to replicate the multidimensionality of TDV as observed in the other measures using exploratory and confirmatory factor analytical approaches. Finally, we aimed to establish concurrent validity with this measure using participants’ ratings of alcohol overconsumption, cannabis use, and rape myth acceptance views as outcome variables.
Materials and Methods
Participants
A total of 730 adolescents between grades 7 and 12 were recruited from high schools in three provinces (i.e., Quebec, Ontario, and Manitoba) in Canada (Mage = 15.88 years, SD = 1.23). Twelve schools participated in the study, four of which were from Quebec, six were from Ontario, and two from Manitoba. Demographic information for the full sample is presented in Table 1. The majority of participants identified their gender as female, followed by male, and non-binary. Half of the sample also identified their ethnicity as White/European (50.1%), and most of the participants did not have previous experiences with relationship violence (90.9%).
Table 1. Demographic information of samples.
Procedure
Ethical approval was obtained from each of the relevant research ethics bodies at the universities and local school boards. The research team first visited each participating school to explain the purpose of the study and administer consent forms. Once a signed guardian consent form was returned, students were asked to provide assent to participate in the study. During the study, participants responded to various questionnaires that lasted approximately 1 h.
Measures
Teen Dating Aggression Measure
We modified the original CADRI to capture adolescent dating violence more adequately and to expand upon the types of violence assessed. Our modification included combining the two items assessing sexual violence to address potential concerns by schools and their respective boards, i.e., “Forced me to have sex with them when I didn’t want to” and “Touched me sexually when I didn’t want them to” were combined into one broad item: “Forced me to do something sexual that I didn’t want to do.” After the original CADRI items, 20 new statements were added that describe additional forms of violence such as coercion (e.g., “Kept pressuring me to do something even after I made it clear that I did not want to”) and control (e.g., “Made me let them read my emails or texts when I didn’t want them to”). For each of the 44 items on the adapted scale, participants rated how often the behavior occurred with a dating partner over the past three months using a Likert scale from 0 (“never”) to 4 (“most days of the week”).
Rape Myth Acceptance
Participants were asked to rate 10 items that assessed how much they agreed with statements regarding rape myths (RMA) on 4-point Likert scale ranging from 1 (“Strongly Disagree”) to 4 (“strongly agree”). Items were adapted from established scales of this construct (e.g., Illinois Rape Myth Acceptance Scale; Payne et al., 1999). Consistent with Dworkin et al. (2017), two scores were computed. The first reflected a measure of traditional gender expectations (e.g., “Girls should have sex with the guy they are dating when he wants”) while the second measured rape denial (e.g., “If a girl is sexually assaulted while drunk, she is to blame”). Items were summed for each score and higher scores indicated greater endorsement of RMA. Cronbach’s alpha for traditional gender expectations (0.81) and rape denial (0.73) were high across both samples.
Cannabis and Alcohol Consumption
Participants were asked to assess how often they used cannabis or marijuana using a 6-point Likert scale, ranging from 1 (“Never”) to 6 (“About 6 or 7 times a week”) (M = 1.48, SD = 1.06). Similarly, alcohol overconsumption in the past month (i.e., drinking to the point of drunkenness) was rated on a 6-point Likert scale, ranging between 1 (“Never”) and 6 (“5 or more times”) (M = 1.22, SD = 0.64).
Plan of Analysis
The analytical plan followed five steps. First, we split the sample using complex sampling procedures (described below). Second, descriptive correlations and inter-item correlations were computed in SPSS to evaluate normality of the data. Third, an EFA of the first sample was conducted. Fourth, CFA to verify the factor structure that was derived from the EFA with the second sample. Finally, bivariate correlations were conducted to examine the associations among the scales and with adolescent rape myth acceptance, and cannabis and alcohol consumption. The EFA and CFA were analyzed with Mplus 8 (Muthén and Muthén, 1998-2017). To evaluate the fit of the models, fit indices suggested by Hu and Bentler (1999) and Kline (2016), which includes the Comparative Fit Index (CFI; values of at least 0.90), the Tucker-Lewis Index (TLI; values of at least 0.95), the Root Mean Squared Error of Approximation (RMSEA; values no greater than 0.08), and the Weighted Root Mean Squared Error of Approximation (WRMR; values no greater than 1.00) were used.
Complex Sampling
In order to examine the factor structure and provide validation, complex random sampling in SPSS was used to split the main sample into two groups. Three strata were used to randomly assign participants into one of the two samples: (a) gender identity, (b) grade level, and (c) previous experience with relationship violence. Sample 1 (S1) was comprised of 353 participants (63.7% female) and Sample 2 (S2) included 377 participants (62.3% female).
Results
Descriptive Statistics
Descriptive statistics including skewness and kurtosis were calculated for each item in both samples (see Table 2). In general, each of the items did not have a mean score above 2 but had skewness and kurtosis values that exceeded |1.50| (Tabachnick and Fidell, 2013). Given that these items were rarely endorsed by the participants, the data were treated as categorical rather than continuous, but maintained the original Likert scale options that were originally posed. Moreover, we conducted a missing values analysis and found that none of the items had a proportion of missing values that exceeded 5% (between 2.10 and 3.00%).
Table 2. Descriptive statistics of items.
Exploratory Factor Analysis
An EFA was conducted on the first sample using the weighted least squares mean and variance adjusted (WLSMV) estimator and the geomin oblique rotation (epsilon = 0.50). Using the eigenvalue-greater-than-1 rule (Kaiser, 1960), results from this analysis suggest a 7-factor model (see Table 3). However, the increase in number of factors could also result in multiple cross-loadings, therefore, we also examined the changes in model fit to determine which factor structure best fit the data. Specifically, we calculated the change (Δ) in RMSEA, CFI, TLI, and SRMR by comparing each model with the model that preceded it. For example, the change in fit for a 2-factor solution was calculated by taking the difference between its fit and the fit from the 1-factor solution. In line with empirical suggestions for factor retention (e.g., Clark and Bowles, 2018), ΔCFI and ΔTLI improvements of at least 0.01 were considered in determining the final factor structure.
Table 3. Exploratory factor analysis (EFA) model fit indices for the factor structure of the Teen Dating Aggression Measure (TeDAM).
Upon examination of change in model fit as well as considering the overall conceptualization of the factors, a 3-factor solution appeared to be the best fitting model (see Table 3). In this model, the change in model fit from a 2-factor solution to a 3-factor solution produced ΔRMSEA = 0.02, ΔCFI = 0.01, ΔTLI = 0.01, and ΔSRMR = 0.01. The change in the subsequent models did not necessarily improve the overall model fit. From there, the factor loadings of the items were evaluated; items that cross-loaded onto more than one factor were dropped if the standardized loading was < 0.32. The correlations between each of the three factors (F1, F2, F3) were statistically significant (p < 0.05): F1-F2 = 0.46, F1-F3 = 0.52, F2 and F3 = 0.50.
Further investigation of the items showed that three items closely cross-loaded (difference between 0.02 and 0.06) onto two factors and did not quantitatively or conceptually fit with the factor in which it strongly loaded (discussed next). The three items were: (a) “Ridiculed or made fun of me in front of other people”; (b) “Told me that he/she would break up with me if I did not do something he/she wanted”; and (c) “Insulted me or said mean things to me when I said ‘no’ to him/her about doing something.” Thus, we removed the items and reanalyzed the EFA, which still supported a 3-factor solution. Table 3 provides fit indices and change (Δ) in model fit between each of the solutions. In this final model, there were fewer cross-loadings; when they did occur, there was discussion of the item in question and consensus was achieved if the authors agreed that it conceptually fit with the factor to which it was primarily loaded. The three factors consisted of constructs related to: (a) psychological aggression, (b) physical, sexual aggression, and (c) relational aggression. Table 4 provides the standardized loadings for each of the three factors.
Table 4. Standardized factor loadings and descriptive statistics for the 3-factor solution of the Teen Dating Aggression Measure (TeDAM).
Factor 1: Psychological Aggression
The first factor was comprised of 17 items, with standardized loadings ranging from 0.37 to 0.82. These items appear to reflect a psychological or manipulative form of aggression perpetrated to victims. Example items include, “gave me the silent treatment,” “insulted me,” “brought up something bad I had done in the past,” and “accused me of flirting with someone else.” The Cronbach’s alpha for this scale was 0.94.
Factor 2: Physical, Sexual Aggression
In the second factor, the standardized loadings of 14 items (factor loadings ranging between 0.42 and 0.87) suggest overt physical and sexual aggression acts committed toward a victim. Example items within this factor include, “threw something at me,” “threatened to hurt me,” “kicked, hit, or punched me,” and “kissed me when I didn’t want him/her to.” Cronbach’s alpha was 0.89.
Factor 3: Relational Aggression
In this last factor, 9 items with standardized loadings ranging between 0.53 and 0.86 reflect an indirectly applied form of relational aggression. In particular, the items reflected behaviors that a partner may do or say to others about a victim. Unlike the first factor that focused on psychological aggression targeted toward a victim, the items on this scale generally involved behaviors that implicated other individuals, such as a victims’ friends. Some examples from this scale include, “talked about how other people were better or more fun than me,” “left me out of an activity or social group on purpose,” “spread rumors about me,” and “said mean things about me to other people.” Cronbach’s alpha for this scale was 0.91.
Confirmatory Factor Analysis
Three separate CFAs were conducted with the second sample to compare a 3-factor model with a 2-factor model and 1-factor model, respectively. Given the use of the WLSMV estimator, the DIFFTEST function was employed using the 3-factor model as the initial comparison against the 2-factor and 1-factor models. In comparison to the 3-factor model, the 2-factor and 1-factor models each had statistically significant worse fit (all ps < 0.001). Thus, we retained the 3-factor model identified from the EFA used with the first sample (see Table 5). In general, model fit was acceptable, χ2(737) = 1611.27, p < 0.001, CFI = 0.94, RMSEA = 0.06 (0.05–0.06); standardized factor loadings were strong (>0.60) and statistically significant (p < 0.001) (see Table 6 for loadings by factor). Further, reliability using McDonald’s omega (ω), which does not assume equal factor loadings (see Hayes and Coutts, 2020), showed that the scales were highly reliable.
Table 5. Confirmatory factor analysis (CFA) model fit for the factor structure of the Teen Dating Aggression Measure (TeDAM).
Table 6. Confirmatory factor analysis standardized loadings and omega reliability estimates (ω).
Mean-Level Differences by Gender Identity and Grade Level
Scores for each of the three dimensions were aggregated for each of the three scales and then compared as a function of participant gender identity and grade level. A one-way MANOVA with the three scores as the dependent variables did not yield a statistically significant multivariate effect of gender identity for Sample 1, Wilk’s λ = 0.97, F(9, 825.19) = 1.31, p = 0.23, ηp2 = 0.01, or Sample 2, Wilk’s λ = 0.97, F(9, 886.03) = 1.28, p = 0.24, ηp2 = 0.01. Additionally, there were no observed multivariate effects of grade level for Sample 1, Wilk’s λ = 0.98, F(12, 894.44) = 0.52, p = 0.90, ηp2 = 0.01, or Sample 2, Wilk’s λ = 0.95, F(18, 1021.55) = 1.00, p = 0.46, ηp2 = 0.02. The lack of significant group differences suggest that the means from each of the three dimensions did not significantly differ as a function of the participant’s gender identity or their grade.
Concurrent Validity
In the last analysis, we tested concurrent associations between the TeDAM, perceptions of rape myths acceptance, cannabis use, and alcohol consumption (see Table 7 for descriptive statistics). Accordingly, bivariate correlations including bootstrapping (n = 10,000) to estimate 95% confidence intervals were computed between the mean scores of the three factors along with cannabis use, alcohol overconsumption, and rape myth acceptance for the whole sample. Results showed similar findings across each of the three factors (see Table 8). Psychological aggression was positively associated with alcohol overconsumption, cannabis use, and rape denial. Physical and sexual aggression was also positively correlated with each of alcohol overconsumption, cannabis use, and rape denial. Similarly, relational aggression was positively related to alcohol overconsumption, cannabis use, and rape denial. There were no statistically significant associations between the TeDAM scales and traditional gender expectations (ps > 0.05).
Table 7. Descriptive statistics of study variables for the overall sample.
Table 8. Bivariate correlations between Teen Dating Aggression Measure (TeDAM) scales and outcome variables.
Discussion
Findings from this study provide initial psychometric support for the TeDAM and its use among adolescents. Specifically, factor analyses for the TeDAM suggested that a solution that included three factors, namely behaviors regarding (a) psychological aggression, (b) physical and sexual aggression, and (c) relational aggression, were most appropriate. This factor structure was further supported in a CFA and high reliability estimates.
Each of the factors represented the various ways in which adolescents might experience dating aggression. The first factor, physical and sexual aggression, is common among all measures within the TDV literature. In line with other measures of dating violence victimization, including the CADRI (Wolfe et al., 2001) and the MARSHA (Rothman et al., 2021), the TeDAM yielded a factor that incorporated elements of physical (e.g., slapped, hair pulled, objects thrown) as well as sexual aggression (e.g., threats to coerce sexual acts, sexual force). The second factor reflected psychological aggression, which are harmful verbal and/or emotional acts directed toward the victim (Follingstad et al., 2005). Previous work by Follingstad (2007) suggests that psychological aggression in the form of humiliation and insults differs from physically aggressive acts. Indeed, the factor structure of the TeDAM supports the claim that dating violence and aggression should not be limited to physical acts. Specifically, psychological aggression included items related to verbal and emotional aggression (e.g., making accusations, insulting, giving the silent treatment) as well as manipulative forms of aggression (e.g., made to allow to read social media, keeping track of a partner). Lastly, the third factor related to acts that were characterized as relational aggression. Although this factor could be interpreted similarly to the psychological aggression, the relational component referred to behaviors pertaining to the implicates the peer group (or others) to harm the relationship. For example, items within this scale included aggressive acts such as spreading rumors or using others (e.g., a victim’s friends) to make threats or exclude a partner. Within the context of adolescent peer relations, psychological forms of aggression are distinct from relational aggression (see Linder et al., 2002). In particular, the target of psychological aggression is the victim while the target for relational aggression is the relationship. The methods employed within each form of aggression can vary, but the target remains consistent. The addition of a scale focused on relational aggression scale is supported by previous research on IPV, in which romantic relational victimization was found to be negatively correlated with romantic relationship quality (Linder et al., 2002).
There were three findings related to the validation of the measure. First, we found that each of the three factors was associated with adolescent cannabis use and the overconsumption of alcohol. Specifically, more frequent experiences with each of the three aggressive factors were associated with increased use of cannabis and drinking. These findings are in line with previous work that suggests that cannabis and alcohol are associated with victimization from TDV and assault (e.g., Dworkin et al., 2017; Johnson et al., 2017). The last two findings refer to the association between the TDV factors and rape myth acceptance. In particular, there were no significant associations with the traditional gender expectations scale, whereas each of the factors were positively correlated with rape denial. Previous studies have shown positive associations between rape myth acceptance and sexual dating aggression (Reyes and Foshee, 2013). Our findings are partially in line with these results, with the exception of traditional gender expectations. There are two potential methodological explanations for this. First, the IRMAS, the measure with which the items were derived and adapted, is known to produce floor effects, which could explain the lack of a significant association (Trottier et al., 2021). Moreover, with the exception of Dworkin et al. (2017), research on the association between TDV victimization and rape myth acceptance and its specific subscales have not been investigated with an adolescent population and therefore requires replication.
Broadly, the strengths of the TeDAM include the support for a scale on relational aggression. This addition is important because it incorporates the typical actions and behaviors that adolescents engage in with their peers as well as their romantic partners, thus making the measure more developmentally relevant. From a measurement perspective, the TeDAM is also straightforward to use, easy to score, and has strong reliability and validity. Nevertheless, this study acknowledges some limitations. First, although the large sample was obtained from three different provinces across Canada, these were not nationally representative, therefore we could not test for sociodemographic differences (e.g., ethnicity). Second, although our sample size was large enough to assess the factor structure of this measure, we were unable to fully evaluate the psychometric properties using measurement invariance, which would address the extent to which the items were interpreted in a similar manner across different groups. As such, replication of the factor structures and an analysis of the equivalence across sex, gender identity, and previous experiences with relationship violence would benefit the utility of the TeDAM. Finally, the present study was focused on dating victimization experiences of youth. However, it is also necessary to consider the extent to which dating partners perpetrate such acts. Given that the additional items were written similarly to the CADRI, we argue that the target of scale can change between the victim to the perpetrator, which would be in line with other measures, including the CADRI (Wolfe et al., 2001) and the MARSHA (Rothman et al., 2021, 2020). We speculate that a similar factor structure would emerge with dating violence perpetrators.
In summary, the goal of this study was to create an assessment of TDV that was designed to reflect the adolescent experience and include relevant forms of TDV. This measure begins to address the gaps in extant TDV measures by including items related to overt sexual violence, psychological aggression, and relationally aggressive behaviors. Results provided initial psychometric support for a developmentally relevant assessment of adolescent aggressive experiences in the context of romantic relationships. Given both the short- and long-term consequences of victimization from dating violence, there are meaningful implications for researchers, as this could provide more authentic findings when investigating the phenomenon of TDV, as well as have important implications for practitioners (e.g., clinicians) looking to obtain a more comprehensive view of the experiences of TDV victimization among the youth they service. Together, with further development and implementation of the TeDAM, this study has crucial theoretical implications as it could help increase our understanding in the field of TDV.
Data Availability Statement
The datasets presented in this article are not readily available because there are ethical and consent restrictions that do not allow for the release of data outside of the research team. Requests to access the datasets should be directed to WC, wendy.craig@queensu.ca.
Ethics Statement
The studies involving human participants were reviewed and approved by 1. Research Ethics Board Office (McGill University) #20-07-044 - Research Ethics, 2. General Research Ethics Board (Queen’s University) #GPSYC-997-20. Written informed consent to participate in this study was provided by the participants’ legal guardian/next of kin.
Author Contributions
WC, MD, AM-S, and CK conceptualized and designed the larger study which includes this study. ND coordinated data collection as well as cleaned the data. For this manuscript, RP, TW, LV-M, and CK contributed to the conceptualization and plan. RP organized the data. RP and LV-M conducted the statistical analyses. RP wrote the first draft of the manuscript. TW, LV-M, and ND wrote sections of the manuscript. CK oversaw the manuscript writing throughout the process. All authors contributed to manuscript revision, read, and approved the submitted version.
Funding
This research was supported by a grant from the Public Health Agency of Canada (1718-HQ-000788) awarded to WC.
Conflict of Interest
The authors declare that the research was conducted in the absence of any commercial or financial relationships that could be construed as a potential conflict of interest.
Publisher’s Note
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Keywords: dating violence, adolescents, aggression, teen dating violence, adolescent dating aggression
Citation: Persram RJ, Wong TKY, Vargas-Madriz LF, Konishi C, Dryburgh NSJ, Dirks MA, Martin-Storey A and Craig W (2021) Development and Validation of the Teen Dating Aggression Measure Among Canadian Youth. Front. Psychol. 12:763210. doi: 10.3389/fpsyg.2021.763210
Received: 23 August 2021; Accepted: 22 November 2021;
Published: 14 December 2021.
Edited by:
Ilaria Grazzani, University of Milano-Bicocca, ItalyReviewed by:
Emanuela Confalonieri, Catholic University of the Sacred Heart, ItalyJennifer Yahner, Urban Institute, United States
Copyright © 2021 Persram, Wong, Vargas-Madriz, Konishi, Dryburgh, Dirks, Martin-Storey and Craig. This is an open-access article distributed under the terms of the Creative Commons Attribution License (CC BY). The use, distribution or reproduction in other forums is permitted, provided the original author(s) and the copyright owner(s) are credited and that the original publication in this journal is cited, in accordance with accepted academic practice. No use, distribution or reproduction is permitted which does not comply with these terms.
*Correspondence: Ryan J. Persram, ryan.persram@mail.mcgill.ca