youth emotional reactivity, interparental conflict, parent hostility, and worrying among children...
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Journal of Child and Family Studies ISSN 1062-1024 J Child Fam StudDOI 10.1007/s10826-015-0280-x
Youth Emotional Reactivity, InterparentalConflict, Parent Hostility, and WorryingAmong Children with Substance-AbusingParents
Michelle L. Kelley, Tyler D. White,Robert J. Milletich, Brittany F. Hollis,Brianna N. Haislip, Erin K. Heidt, CassieA. Patterson, et al.
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ORIGINAL PAPER
Youth Emotional Reactivity, Interparental Conflict, ParentHostility, and Worrying Among Children with Substance-AbusingParents
Michelle L. Kelley1 • Tyler D. White1 • Robert J. Milletich1 • Brittany F. Hollis1 •
Brianna N. Haislip1 • Erin K. Heidt1 • Cassie A. Patterson1 • James M. Henson1
� Springer Science+Business Media New York 2015
Abstract The present study examined whether emotional
reactivity mediated the association between interparental
violence, parental hostility, and children’s worrying among
90 youth living with substance-abusing parents. Children
completed measures of security and anxiety. Mothers and
fathers’ completed measures of violence perpetrated
toward their partners and general hostility. Results of a
Bayesian mediation model revealed indirect effects such
that after controlling for other variables in the model,
fathers’ hostility was associated with greater emotional
reactivity, which in turn was associated with children’s
reports of worrying. The indirect effects of mothers’ hos-
tility, parents’ interparental violence, and child age on
children’s reports of worrying via children’s emotional
reactivity were not statistically significant. Results suggest
that fathers’ hostility is associated with children’s reports
of worrying among children residing with a substance-
abusing parent via associations with children’s emotional
reactivity to parental conflict.
Keywords Interparental violence � Parent hostility �Children’s anxiety � Children of substance-abusing parents
Introduction
Children of substance abusers (COSAs) are at greater risk
for internalizing symptoms such as anxiety (Billick et al.
1999; Eiden et al. 2009; Hussong et al. 2008; Wilens et al.
2002). Both interparental violence (e.g., Bergman et al.
2014) and to a lesser extent, chronic exposure to parental
hostility (e.g., Berman et al. 2000), are associated with
children’s tendencies to worry. Emotional reactivity, which
involves habitual elevation of arousal and dysregulation of
children’s emotions (Davies and Cummings 1994) in
response to interparental conflict and parent hostility are
likely to contribute to children’s anxiety; however, these
processes have received little attention among youth living
with substance-abusing parents.
The larger developmental literature has demonstrated
ties between interparental violence and children’s inter-
nalizing difficulties (e.g., Evans et al. 2008; Ingram and
Luxton 2005). For instance, Kitzmann et al. (2003) found a
significant association between exposure to interparental
violence and children’s somatic complaints. In a meta-an-
alytic study, Buehler et al. (1997) found an average effect
size (d-value) of 0.35 for parents’ use of an overt parental
conflict style (which included physical violence and verbal
aggression) and youth internalizing and externalizing
problems.
Not only do COSAs experience high levels of anxiety
(e.g., Hussong et al. 2008), but parental substance abuse
may impede recovery from anxiety as adults. For instance,
in a longitudinal study of young adults with some form of
anxiety disorder, parental anxiety disorder did not predict
participants’ relapse from anxiety disorders; however,
those with a history of parental substance use were twice as
likely go from asymptomatic to symptomatic panic disor-
der or social phobia over the course of the study (Pagano
et al. 2007).
One reason parental substance abuse is highly tied to
children’s internalizing symptoms (e.g., Eiden et al. 2009;
Hussong et al. 2008) may be that interparental violence is
common among parents with substance use disorders (see
& Michelle L. Kelley
1 Department of Psychology, Old Dominion University,
Norfolk, VA 23529-0267, USA
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DOI 10.1007/s10826-015-0280-x
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Kelley et al. 2010 for a review; Stover and Kiselica 2014).
In fact, approximately 50–65 % of adults entering sub-
stance abuse treatment report past-year partner violence
(e.g., Burnette et al. 2008; Chermack et al. 2001; Chermack
et al. 2010; Kaufmann et al. 2014; see Murphy and Ting
2010, for a review). Moreover, the association between
intimate partner violence and substance abuse has been
demonstrated for alcohol (Foran and O’Leary 2008; Moore
et al. 2011; Shorey et al. 2014), cocaine (Norlander and
Eckhardt 2005), opioids (El-Bassel et al. 2007; Subodh
et al. 2014), and alcohol and cocaine or marijuana (Crane
et al. 2014; Kraanen et al. 2014).
Relative to interparental violence and youth anxiety,
previous studies have paid less attention to psychopathic
traits such as general hostility among parents that may also
contribute to the development of internalizing symptoms.
Patterson et al. (2000) contend that hostile interactions in
families undermine effective responses to children. Like-
wise, Denham et al. (2000) described parent hostility as a
form of chronic distress that may diminish parents’ ability
to respond effectively to children’s behavior and needs. In
a subset of children in the Denham et al. sample who had
elevated externalizing behavior scores, mothers’ supportive
behavior and less anger, and fathers’ reports of lack of
hostility and anger, discriminated between youth whose
behavior problems diminished or increased 5 years later. In
a sample of fathers who had been arrested for domestic
violence, there was a tendency for men’s interpersonal
hostility to be associated with their reports of their chil-
dren’s overall emotional and behavioral functioning (Fe-
bres et al. 2014). In a community sample, emotional
dysregulation and self-blame mediated the association
between interparental hostility measured when children
were in sixth grade and youth internalizing problems
2 years later (Buehler et al. 2007). Correspondingly, parent
hostility was one of the best predictors of youth who
recovered from phobic and anxiety disorders after receiv-
ing exposure-based cognitive and behavioral treatment as
compared to children who did not (Berman et al. 2000).
Research examining associations between parent hos-
tility and anxiety among COSAs is rare. Hostility is asso-
ciated with drug and alcohol use (Calhoun et al. 2001;
Hamdan-Mansour et al. 2009; Hampson et al. 2010; Stover
and Kiselica 2014). Furthermore, both cocaine (e.g., Parrott
et al. 2003; Roozen et al. 2011) and alcohol (e.g., Eckhardt
2007; Giancola et al. 2002) administration studies have
documented increases in negativity and hostility. More-
over, adult children of alcoholics (ACOAs) are more likely
than non-ACOAs to report their parents as hostile,
uncontrolled, and rejecting (MacPherson et al. 2001). It is
possible that the overt hostile style of interparental conflict
described by Ahrons (1981) and Camara and Resnick
(1988) depicts many substance-abusing couples and may
impact children’s internalizing symptoms (Buehler et al.
2007; Denham et al. 2000). Extrapolating from the larger
literature with children of non-substance-abusing parents,
general hostility may be essential to understanding why
some COSAs develop internalizing symptoms such as
worrying.
A prominent theory, the emotional security hypothesis
(EST; Cummings and Davies 2010; Davies and Cummings
1994), holds that children develop a sense of security from
their developmental contexts. When their emotional secu-
rity is threatened by family processes, particularly hostile,
threatening interparental behavior, children may be affec-
ted in many ways. Constant threats from interparental
conflict may deplete children’s coping resources and result
in disrupted physiological responses (Cummings et al.
2006; Davies et al. 2006). Over time, children exposed to
interparental violence decrease their ability to regulate
feelings of fear, worry, and increase vulnerability to
internalizing problems (Bergman et al. 2014). In contrast,
children who are better able to maintain emotional regu-
lation in the midst of family violence and other hostile and
threatening behaviors should be less likely to experience
symptoms of emotional anxiety (Cummings and Davies
2010). Considerable research, primarily with community
samples, has found emotional insecurity accounts for the
relationship between interparental conflict and children’s
(Davies and Forman 2002) and adolescents’ (Bergman
et al. 2014) internalizing symptoms.
Although relatively few studies have examined inter-
parental violence, parent characteristics, and emotional
regulation in COSAs, Ballard and Cummings (1990) found
children of problem drinking parents (COAs) were more
likely to become involved in marital conflicts than non-
COAs. Keller et al. (2007) found when mothers were the
identified problem drinker children were more likely to
intervene in response to escalating interparental conflict
that was about child caretaking. In contrast, exposure to
paternal problem drinking was related to child mediation
and avoidance when parents were arguing about the child,
and no response to escalated conflict. Some (Fergusson and
Horwood 1998), but not all research (El-Sheikh et al. 2008)
with community samples has found children’s emotional
security may be more threatened in instances of male-to-
female aggression. It is possible that the degree to which
youth report emotional reactivity during parent conflict
may vary by whether violence is male-to-female or female-
to-male and mothers’ versus fathers’ hostility.
In the present study, we tested whether mothers’ and
fathers’ reports of the perpetration of interparental violence
and psychopathological symptoms of hostility were indi-
rectly associated with their children’s reports of worrying.
We hypothesized that fathers’ and mothers’ interparental
violence perpetration and hostility would be associated
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with youth reports of worrying via increases in emotional
reactivity during parental conflicts.
Method
Participants
Participants were 90 triads (90 fathers, 90 mothers, and 90
children) in which one or both parents met drug, alcohol, or
both drug and alcohol disorder criteria for alcohol or drug
abuse (4th ed., text rev.; DSM-IV-TR; American Psychi-
atric Association 2000). Families were recruited from
advertisements to take part in a larger study in which eli-
gible couples could receive substance abuse treatment.
Data are reported here on the pretreatment assessment.
Families did not differ on background variables reported in
Table 1 as a function of type of substance abuse (i.e., drug
use only, drug and alcohol abuse, or alcohol abuse) or
whether one or both parents met substance abuse criteria.
Families were excluded if (a) the child had cognitive,
physical, or psychological limitations that would preclude
their ability to understand the questions, (b) partners did
not reside together, (c) the child did not reside with parents
full-time (or in a few instances the child resided with the
parent part-time but on a regular basis such as alternating
weeks and the study parent maintained joint custody of the
child), or (d) any family member was not fluent in English.
In the case of families with more than one child in the age
range, to prevent selection bias, the child with the closest
birthday to the initial screening was invited to participate.
Parents gave approval for themselves and their children to
participate. Children gave assent. Family members were
compensated $90.00 ($30.00 each).
The mean age for fathers was 39.84 years (SD = 7.84);
the mean age for mothers was 38.22 years (SD = 7.42).
The majority of parents were White. The mean age for
children was 11.08 years (SD = 3.81; range 6–18 years);
Table 1 Demographics for
sampleVariable Mother Father
Count (%) Mean SD Count (%) Mean SD
Age in years – 38.22 7.42 – 39.84 7.84
Ethnicity
African-American 15 (16.67) – – 21 (23.33) – –
American Indian or Alaskan Native 2 (2.22) – – 4 (4.44) – –
Asian 1 (1.11) – – 0 (0.00) – –
Caucasian 55 (61.11) – – 52 (57.78) – –
Hispanic or Latino 3 (3.33) – – 7 (7.78) – –
Multicultural/other 14 (15.56) – – 6 (6.67) – –
Married
Yes 48 (53.33) – – 48 (53.33) – –
No 42 (46.67) – – 42 (46.67) – –
Years cohabitating – 9.13 7.05 – 9.13 7.05
Years of education – 13.53 2.38 – 12.70 2.41
Income (past 6 months)
\$20,000 61 (67.78) – – 48 (53.33) – –
$20,000–\$40,000 17 (18.89) – – 19 (21.11) – –
$40,000–\$60,000 7 (7.78) – – 11 (12.22) – –
[$60,000 3 (3.33) – – 12 (13.33) – –
Missing 2 (2.22) – – 0 (0.00) – –
SUD diagnosis
None 47 (52.22) – – 7 (7.78) – –
Alcohol only 10 (11.11) – – 19 (21.11) – –
Drug only 10 (11.11) – – 15 (16.67) – –
Alcohol and drug 23 (25.56) – – 49 (54.44) – –
Child age in years – 11.08 3.81 – 11.08 3.81
Child sex
Male 44 (48.89) – – 44 (48.89) – –
Female 46 (51.11) – – 46 (51.11) – –
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46 children were girls. See Table 1 for additional
sociodemographic information.
Procedure
After a brief initial phone screening to determine if the
family met general study criteria and determine whether
both partners and children were interested, a convenient
time was set to meet for the assessment. At this meeting,
the study was described in detail and partners were indi-
vidually consented and gave permission for their children
to participate. Parents were individually and separately
administered the SCID (First et al. 2010) by a licensed
mental health counselor or psychologist with 5–15 years of
clinical substance abuse research experience. Each parent
then independently and separately completed the self-re-
port instruments. In several instances, after the initial
phone screening, the SCID was administered by a trained
research assistant. The counselor or clinical psychologist
reviewed the SCID prior to determining substance use
diagnosis. Children give assent and then were administered
questionnaires privately from their parents. Care was given
to ensure that children adequately understood the ques-
tions. This included asking children to restate the instruc-
tions, encouraging questions, and having children complete
sample items. The study was conducted in accordance with
the code of ethics of the American Psychological Associ-
ation and human subjects approval was granted by the
participating research university prior to participation.
Measures
Security in the Interparental System (SIS; Davies et al.
2002)
Children were administered the 9-item Emotional Reac-
tivity subscale from the SIS. The SIS assesses children’s
strategies for preserving emotional security in the context
of parent conflict. Specifically, after a brief preface chil-
dren answer each question reflecting how they felt during
the past year [e.g., ‘‘When my parents argue, I feel (sad,
scared, angry, unsafe); After my parents argue, (it ruins my
whole day, I can’t seem to calm myself down, I can’t seem
to shake off my bad feelings); ‘‘When my parents have an
argument, I try to hide what (I’m feeling, I can’t stop
thinking about their problems)]. Response choices were (1)
not at all true of me, (2) a little true of me, (3) somewhat
true of me, and (4) very true of me. Test-retest reliability
over a 6 months period for the SIS was 0.87 among sixth,
seventh, and eighth graders, and validity has been shown in
relation to children’s responses to conflict across different
informants, conflict stimuli, and more than one occasion
(Davies et al. 2002). For the present study, alpha was 0.89.
Revised Children’s Manifest Anxiety Scale (RCMAS;
Reynolds and Richmond 1978)
The RCMAS is a 37 item scale designed to assess the level
and nature of children’s anxiety. Scores for four subscale
scores can be derived (i.e., worry/oversensitivity, physio-
logical anxiety, concerns/concentration, and a lie scale).
For the present study we examined scores from the Worry
(e.g., ‘‘I worry a lot of the time’’ ‘‘My feelings get hurt
easily’’; 11 items) dimension. Children respond to each
item ‘yes’ or ‘no’. Affirmative responses are given 1 point;
negative scores are given 0 points. Because scores are
derived from affirmative responses, high scores reflect
greater worrying. In a community sample of children ages
8 to 16, Schudlich and Cummings (2007) found internal
consistency of the RCMAS of 0.90. Internal consistency
for the Worry scale was 0.83 in the present study.
Symptom Checklist-90-Revised (SCL-90-R; Derogatis
1994)
Mothers and fathers completed the SCL-90, a 90-item
questionnaire that assesses symptom dimensions. For the
purpose of the present study, six items that assess hostility
(e.g., ‘‘Temper outbursts that you could not control’’,
‘‘Having urges to beat, injure or harm someone’’,
‘‘Shouting or throwing things’’). Items are scored on a
5-point scale from (0) not at all, to (4) extremely. Schmitz
et al. (2000) found reliable change and clinical significance
of the SCL-90 in normative and clinical samples, with an
overall SCL-90 alpha of and 0.78 for the hostility subscale.
In a study of treatment outcomes of children exposed to
interparental violence, Lieberman et al. (2005) reported
subscale alphas for the SCL-90 between 0.77 and 0.90.
Internal consistency for the hostility dimension of the SCL-
90-R was 0.80 and 0.81 for mothers and fathers,
respectively.
Conflict Tactics Scale-2 (CTS2; Straus et al. 1996)
To assess interparental violence, both parents completed
the Physical Assault and Injury subscales of the CTS2. The
CTS2 assesses the frequency with which each partner
perpetrated and were victims of various physical violence
(e.g., hit, slapped, slammed against a wall), in the past year.
Response choices were 0 (never), 1 (once), 2 (twice), 3 (3–
5 times), 4 (6–10 times), 5 (11–20 times), 6 (more than 20
times), or 7 (not in the past year, but it did happen before).
Responses of 7 (not in the past year, but it did happen
before) were recoded as 0. For the present study, item
responses were summed to obtain total scores for fathers’
reports of father-to-mother perpetration of violence and
mothers’ reports of mother-to-father perpetration of
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violence. The CTS2 has been used in over 600 studies of
family violence (Straus 2007). Internal consistency was
0.90 for mothers and 0.89 for fathers.
Data Analyses
The hypothesized mediation model was tested with Baye-
sian methods using a Gibbs sampler algorithm in Mplus
7.2. A Bayesian approach was used, as opposed to boot-
strapping, to test for the significance of indirect effects
given that Bayesian inferences in small samples are exact
(Yuan and MacKinnon 2009) and Bayesian methods tend
to have lower Type I error rates than bootstrapping
(Koopman et al. 2014). Diffuse priors were specified for
regression coefficients and variances with three indepen-
dent chains using 20,000 iterations (see Asparouhov and
Muthen 2010 for technical details). The first 10,000 itera-
tions were treated as a burn-in phase, which are iterations
not used to represent the posterior distribution.
Model fit was evaluated using a 95 % confidence
interval for the model Chi square (v2), which is a statistic
that represents the difference in v2 values for the real and
replicated data. Good model fit is indicated by a negative
lower limit and a large posterior predictive p value (As-
parouhov and Muthen 2010). Model convergence was
assessed using potential scale reduction (PSR) statistics and
trace plots. PSR statistics compare the parameter variation
within each chain to the parameter variation between
chains to determine if the chains converge to the same
values. The PSR criterion essentially requires the between-
chain variation to be small relative to the total of between-
and within-chain variation (Asparouhov and Muthen
2010). Typically, convergence is satisfied is the PSR is
close enough to 1 for each parameter. Trace plots are used
to visually inspect if a Markov Chain Monte Carlo algo-
rithm (i.e., Gibbs sampler for this data) converges to the
target posterior density and mixes well throughout the
support of the target posterior density. A trace plot that
shows no upward or downward trend in the parameter
draws across each chain provides evidence for convergence
to the target posterior distribution (Yuan and MacKinnon
2009). Similarly, trace plots that show the parameter draws
varied around the support of the target posterior density
provide evidence that the chains mixed well (Gelman et al.
1995).
Autocorrelation plots were used to examine the degree
of correlatedness of parameter values across iterations for
different lags. Small autocorrelations (i.e., \0.1) indicate
approximately independent draws from the posterior dis-
tribution, which is a desired result (Asparouhov and
Muthen 2010). Missing data were imputed internally under
the hypothesized model. Due to the small sample size, the
median was used as a point estimate. Significance testing
for direct and indirect effects was done using 95 % highest
posterior density (HPD) intervals.
Results
As shown in Table 2, the typical child answered affirma-
tively to 4.30 (SD = 3.16) of 9 symptoms of worrying. On
average, children reported the emotional reactivity items
were ‘‘a little true of me’’. Fathers and mothers typically
endorsed at least some level of four or five psychopathologic
symptoms of hostility such as temper outbursts and shout-
ing or throwing things, M(fathers) = 4.09, SD = 4.40;
M(mothers) = 5.24, SD = 4.28. On average, fathers’
reported two acts of male-to-female violence in the previous
year, M(fathers = 1.89; SD = 3.23); mothers’ reported four
instances of female-to-male violence in the previous year,
M(mothers = 3.96, SD = 5.56). Table 2 also presents cor-
relations and means and SD between study variables.
Results of the mediation model demonstrated that the
model provided a good fit to the data, 95 % CI for the
model v2 (-21.468, 28.826) (p = 0.418). Examination of
autocorrelation plots revealed that all autocorrelations were
\0.1, which indicates approximately independent draws
from the posterior distributions. All PSR statistics were
\1.022, trace plots for each parameter showed stability in
parameter values across each chain, and the chains
appeared to mix well across values of the parameter spaces,
all of which provide evidence for model convergence
(Gelman et al. 1995).
Indirect effect analyses revealed that after controlling
for parental IPV perpetration, mother’s hostility, and
child’s age, father’s hostility was associated with higher
levels of children’s emotional reactivity, which in turn was
associated with higher levels of children’s worrying
symptoms, B = 0.120, 95 % HPD interval (0.019, 0.230)
(see Table 3). On the contrary, while controlling for other
variables, the indirect effects of the exogenous variables
mother’s hostility, mother-to-father physical IPV perpe-
tration, father-to-mother physical IPV perpetration on
children’s worrying symptoms via children’s emotional
reactivity were not statistically significant. These null
effects are due to the lack of direct effects between the
exogenous variables and children’s emotional reactivity
(i.e., the mediating variable). Figure 1 presents the fitted
hypothesized mediation model.
Discussion
Despite calls for research on drug-abusing fathers (e.g.,
McMahon et al. 2005), relatively few such studies have
appeared. Furthermore, studies of children’s anxiety focus
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on mothers’ influences (Kim et al. 2009). Moreover, par-
ents underestimate their children’s worry and anxiety
(Lagattuta et al. 2012) and children’s ratings of the inter-
nalizing symptoms have been shown to be reliable
(Michael and Merrell 1998). Therefore, children rated their
own symptoms of anxiety and emotional reactivity. Our
focus is particularly appropriate given that studies consis-
tently find higher rates of internalizing problems among
COSAs (e.g., Hussong et al. 2008). In addition, COSAs are
likely to be exposed to family influences that have been
associated with anxiety among children in community
samples (e.g., Bergman et al. 2014; Davies and Forman
2002; Harold et al. 2012).
Controlling for mothers’ hostility and both parents’
reports of interparental violence, fathers’ accounts of hos-
tility were associated with COSAs’ reports of worrying.
This finding supports research demonstrating that chil-
dren’s ability to regulate their emotions may serve to
mediate the effects of parental hostility on children’s
anxiety in community (Bergman et al. 2014; Davies et al.
2002; Koss et al. 2013) and clinical (e.g., Graham-Ber-
mann 1996) samples. Berman et al. (2000) found parent
hostility was one of the best predictors of youth who
recovered from phobic and anxiety disorders after receiv-
ing exposure-based cognitive and behavioral treatment as
compared to children who did not. Related to the Berman
et al. findings, we found parent hostility in substance-
abusing fathers was associated with their children’s reports
greater emotional reactivity during parent conflicts and
contributed to youth reports of worrying. Thus, among
children residing with substance-abusing parents, fathers’
reports of hostility may be expected to be associated with
children’s emotional reactivity, which in turn may con-
tribute to children’s reports of worrying.
The stronger impact of paternal hostility on youth
reports of worrying via emotional reactivity during inter-
parental conflict may reflect that nearly all fathers met
criteria for drug or drug and alcohol use. Taft et al. (2010)
found drug use was associated with hostility and antisocial
behavior in men. Furthermore, even among substance-
abusing adults who are not typically hostile, during periods
of withdrawal, parents may exhibit irritability, anger, and
hostility (Hanson 2009). In addition, it is possible that
fathers may stimulate more fear than mothers due to their
Table 2 Descriptive statistics
among study variablesVariable 1 2 3 4 5 6 7
1. Child: worry symptoms (0.827)
2. Child: emotional reactivity 0.568 (0.855)
3. Child: age in years 0.083 -0.139 –
4. Father: hostility 0.094 0.301 -0.107 (0.820)
5. Mother: hostility 0.063 0.198 -0.031 0.193 (0.794)
6. Father: IPV perpetration -0.116 -0.088 0.055 0.211 0.201 (0.881)
7. Mother: IPV perpetration -0.175 -0.065 -0.059 0.138 0.397 0.342 (0.904)
Mean 4.301 18.425 11.083 4.098 5.243 1.893 3.976
SD 3.160 7.305 2.784 4.402 4.288 3.237 5.563
Skewness 0.634 0.698 0.162 1.546 0.720 1.902 1.905
Kurtosis -0.527 -0.678 -1.091 2.276 -0.418 3.255 3.766
Missing data % 11.111 8.889 0.000 18.889 20.000 13.333 6.667
Cronbach’s alphas are presented along the diagonal in parentheses. Correlations are presented below the
diagonal. Bold correlations indicate statistical significance at a = 0.05 (the frequentist perspective). Aside
from Cronbach’s alphas, statistics were estimated using full-information maximum likelihood
Table 3 Bayesian estimates of
indirect effectsIndirect effect B 95 % HPD interval
LL UL
Father: H ? child: ER ? child: W 0.120 0.019 0.230
Father: IPV ? child: ER ? child: W -0.074 -0.230 0.061
Mother: H ? child: ER ? child: W 0.092 -0.013 0.218
Mother: IPV ? child: ER ? child: W -0.049 -0.143 0.044
The median was used as a point estimate
HPD highest posterior density, H hostility, ER emotional reactivity, W worry symptoms of anxiety, IPV
intimate partner violence perpetration
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comparable physical strength and size and the pitch and
inflection of their voice (Horn and Sylvester 2002).
Because nearly all fathers had substance use disorder,
children may have had more opportunities to see situations
in which the fathers’ hostility played out in the family
context (e.g., during periods of high use), thus, contributing
to greater emotional reactivity and symptoms of worry.
In contrast to our predictions, controlling for other
variables in the model, mothers’ hostility did not contribute
to children’s emotional reactivity. Furthermore, while the
association between mothers’ hostility and children’s
anxiety was in the expected direction, this association was
not significant. It should also be noted that less than half of
mothers had substance use disorder. Relative to fathers,
mothers generally have larger caregiving roles in their
children’s lives (Jacobs and Kelley 2006). Even substance-
abusing women living with another adult are typically their
children’s primary caregivers (Stewart et al. 2007). Thus,
mothers’ hostility may have less association with
children’s emotional reactivity and worrying because
children may have more opportunity to develop emotional
security with their mothers who typically provide much of
their care. The lack of an association between hostility in
mothers and children’s emotional reactivity during parental
conflict may reflect that maternal hostility may elicit less
fear or concern among children. In addition, some have
also argued that drug and alcohol use may have different
etiology for women versus men. For instance, men with
drug and alcohol use disorder are more likely to have
antisocial personality disorders, whereas women’s drug
and alcohol use may stem from relationship dissatisfaction,
anxiety and depression (e.g., Grella et al. 2009). Gender
differences in caretaking, as well as possible differences in
the etiology maternal and paternal drug use, and that nearly
all fathers met criteria for substance abuse, may account for
the finding that fathers’ hostility contributed to children’s
symptoms of worrying via greater emotional reactivity
during interparental conflict.
Father: Hostility
Mother: Hostility
Child: Emotional Reactivity
Child:Worry
Symptoms
-0.068 [-0.197, 0.067]
0.255[0.166, 0.346]
Father: IPV
perpetration
Mother: IPV
perpetration
Child:Age
-0.022 [-0.230, 0.180]
-0.034[-0.192, 0.116]0.009
[-0.160, 0.176]
0.130 [-0.035, 0.293]
-0.198 [-0.559, 0.149]
-0.298[-0.843, 0.252]
0.373 [-0.039, 0.816]
0.482 [0.116, 0.870]
-0.200 [-0.616, 0.223]
R 2 = .211[.064, .378]
R 2 = .406[.239, .575]
Fig. 1 Fitted mediation model. Numbers are unstandardized median
parameter estimates; 95 % highest posterior density intervals are
presented in brackets below point estimates. Bold indicates statistical
significance at a = 0.05. Covariances among exogenous variables are
omitted for clarity
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Of note, mothers and fathers’ reports of hostility were
not correlated. The lack of correlation between mothers’
and fathers’ hostility is in contrast to what might be
expected based on spillover theory (Erel and Burman
1995). According to this theory, one parent’s hostility
should ‘spillover’ and influence the other partner and for
that matter, other aspects of the family environment.
After controlling for other variables in the model, par-
ents’ reports of the perpetration of violence toward their
partners was not associated with either children’s emo-
tional reactivity to interparental conflict or children’s
reports of worrying. There are a number of possible reasons
for this finding. First, approximately half of couples
reported no interpartner violence. Among those who
reported interparental violence, most couples reported
common couple violence (i.e., pushing or shoving one’s
partner, grabbing one’s partner, slapping one’s partner) as
opposed to patriarchal terrorism (i.e., violence that is typ-
ically male-to-female and involves more control typically
by the male partners and greater potential for or actual
injury such as beating up one’s partner (Johnson 1995). It is
possible that common couple violence may elicit less
emotional arousal among COSAs. Furthermore, mothers’
mean violence perpetration scores were nearly twice that of
fathers. This finding was not unexpected as Caetano et al.
(2001) found non-substance-abusing women perpetrated
twice as many acts of violence than their alcohol-abusing
male partners. It is also important to note that parents’
reported on interparental violence which may not reflect
what children actually saw or heard.
Clinical Implications
While providing services to children who live with sub-
stance-abusing parents may be ideal, parents in need of
substance abuse treatment are reluctant to allow their
children to receive any type of family or individual mental
health treatment (Kelley et al. 2014). At present, parenting
components are rarely part of adult treatment for drug and
alcohol addiction. While it may be a slow process until the
mental health professional is able to broach some of the
deeper family problems, assessing for paternal hostility and
directly approaching the impact that paternal hostility may
have on the emotional reactivity and anxiety symptoms of
children in their homes is of clear importance.
In other instances, COSAs may come to the attention of
teachers and school counselors who suggest the child
receive mental health services or the child’s behavior may
be the catalyst that brings the family into treatment. In
these situations, it may be possible to gain the trust of the
family by first working with the child. After gaining the
trust of the parents, it may be possible to examine the
impact that family functioning, and particularly fathers’
hostility, may play in their children’s anxiety.
Study Limitations
Although the present findings add to our understanding of
anxiety among COSAs, several limitations need to be
considered when interpreting these results. The sample was
comprised of triads in which married or cohabitating two-
parent families were living with their children. Although
this family dynamic may be the most common way that
children are exposed to parental substance use disorder,
results may not generalize to single-parent families or
COSAs who live with extended family members. Also,
families agreed to take part in the preassessment, and
importantly, as part of the larger study, they agreed to come
to couples therapy. This may not reflect couples who are
not interested in substance abuse treatment.
In addition, parents were recruited to the study that met
substance use disorder criteria for any number of drugs or
alcohol use combinations. The sample size prohibited fine-
grained analysis of different forms of alcohol or drug use as
related to parents’ or children’s adjustment. Ideally, future
research should examine how addiction to various sub-
stances may be differentially associated with children’s
internalizing symptoms. Additionally, all data were col-
lected contemporaneously using correlational analyses.
Thus, causal inferences cannot be inferred. Also, we did
not examine whether children had experienced abuse or
neglect, both may be related to children’s emotional
adjustment. Furthermore, we did not examine protective
factors that may be able to facilitate adaptive functioning in
the face of risk (Martinez-Torteya et al. 2009).
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