Note. M (SD ) for continuous variables, n(%) for categorical variables.
As stated in Hypothesis 1, we first tested for a longer duration of
treatment and more use of trauma-specific interventions in the trauma
group. There was no significant effect in the expected direction in the
number of therapy sessions (t (338) = 0.12,pBonf. = .905, d = -0.01) and the duration
of therapy in months (t (338) = 0.75,pBonf. > .999, d = 0.08).
Likewise, Fisher’s exact test revealed no differences in the use of
trauma-unspecific measures to intensify therapy (psychiatric medication:OR = 0.90, pBonf. > .999,
inpatient treatment: OR = 1.01, pBonf.> .999, non-medical social support: OR = 0.90,pBonf. > .999).
Among the trauma-specific interventions, schema mode interventions were
most frequent (22.94%), while trauma-focused interventions (6.47%) and
other, not further specified interventions (3.53%) were rare. Only
skills training was used significantly more often in the trauma group
than in the no-trauma group (OR = 2.47,pBonf. = .019); see Figure 1. For trauma-focused
interventions (OR = 2.73, pBonf. = .137)
and other, not further specified interventions (OR = 5.04,pBonf. = .103), probabilities were descriptively
higher in the trauma group but did not reach significance. For
self-calming techniques (OR = 0.89, pBonf.> .999) and schema mode interventions (OR = 0.96,pBonf. > .999), the probability was
not higher in the trauma group than in the no-trauma group. The
probability for at least one trauma-specific intervention was not
significantly higher for the trauma group than the no-trauma group
(OR = 1.29, p = .150).