DEPRESSION AND ANXIETY 6:133–139 (1997)
Research Articles
MEASUREMENT OF PANIC DISORDER BY A MODIFIED
PANIC DIARY
Edwin de Beurs, Ph.D.,* Dianne L. Chambless, Ph.D., and Alan J. Goldstein, Ph.D.
The psychometric characteristics of panic diary measures were investigated in
a sample of 37 patients suffering from panic disorder with agoraphobia. Following recommendations made in the recent consensus development conference
on the assessment of panic disorder, daily ratings included not only the occurrence of panic attacks but also fear of panic, expectancy of panic, and expected
aversiveness of panic. These new measures were reliable and, on the whole,
demonstrated good divergent and convergent validity. Further, adding such
measures increased the incremental validity of panic disorder assessment.
Depression and Anxiety 6:133–139, 1997. © 1997 Wiley-Liss, Inc.
Key words: panic attack; self-monitoring; fear of panic; panic expectancy
P
INTRODUCTION
anic attacks are the most striking feature of panic
disorder. Consequently, assessment of panic frequency
is considered essential for research on the psychopathology and the treatment of panic disorder (see Shear
and Maser, 1994). For example, investigators often describe the percentage of patients in a treatment trial
who reported no panic during a posttreatment monitoring period (e.g., Cross-national collaborative panic
study, 1992). Although reporting panic frequency is essential, there are two reasons it is not sufficient. First,
panic is but one feature of the disorder (see, e.g.,
American Psychiatric Association, 1994). Other defining features include persistent concerns about having
additional attacks and worry about the possible consequences of an attack, such as insanity or death. Therefore, merely measuring frequency of panic is inadequate
for proper assessment of this disorder. Second, measuring panic frequency is a complicated endeavor. Attacks
typically occur unpredictably, and their frequency may
fluctuate considerably over time—hardly desirable
properties from a psychometric perspective. The instability of panic is especially marked for patients who
suffer agoraphobic avoidance, the majority of panic sufferers who seek treatment (McNally, 1994). To some
degree agoraphobic patients are successful in avoiding
panic. Such patients may have a very low rate of panic
before treatment and report increased panic only when
their avoidance pattern is challenged by in vivo exposure (Cox et al., 1991; Craske and Barlow, 1988; de
Beurs et al., 1993). For these patients, panic frequency
per se is particularly deficient as the sole measure of
their panic symptoms.
© 1997 WILEY-LISS, INC.
Panic disorder experts who attended the recent consensus development conference on the assessment of
panic disorder (organized by the National Institute of
Health) concluded that it is essential for investigators
to measure an additional characteristic of panic disorder, so-called anticipatory anxiety (Shear and Maser,
1994); that is, apprehension about having another
panic attack. Conferees further suggested that this
construct be broken down in two components: (1) expectancy of having a panic attack; and (2) thinking that
an attack is a terrible thing (and therefore something
to be anxious about). Theoretically, different treatment modalities might have differential effects on
these two aspects of panic. For example, pharmacological treatments might lower expectancy of panic
while leaving patients frightened of what might happen to them if they were to panic. On the other hand,
cognitive–behavioral therapy might teach patients to
view panic as less catastrophic, but have less impact on
their expectancy of panic. To capture these concepts,
new measures need to be added to ones now in use.
University of North Carolina at Chapel Hill, Chapel Hill,
North Carolina
Contract grant sponsor: NIMH; Contract grant number: R21MH49851.
*Correspondence to: Edwin de Beurs, Dept. of Psychiatry, Vrije
Universiteit, Valeriusplein 9, 1075 BG Amsterdam, The Netherlands.
Received for publication 17 December 1997; Accepted 12 January 1998
134
de Beurs et al.
Consensus conference experts (Shear and Maser,
1994) concluded that panic diaries were essential for
measurement of the frequency of panic and related concerns. In such daily diaries, patients are asked to monitor
the occurrence of each attack along with additional information. Rapee and Barlow (1991) provide a comprehensive description of a representative diary. Panic
assessment research findings suggest that continuous
monitoring of panic yields more accurate and conservative data than retrospective estimates of panic frequency
gleaned from self-report questionnaires or clinical interviews (de Beurs et al., 1992; Margraf et al., 1987;
Rapee et al., 1990). Nonetheless, little has been done to
examine the psychometric aspects of panic diaries. Such
is the focus of the current study.
In the context of a clinical trial evaluating treatments
for panic disorder with agoraphobia, patients kept a
panic and anxiety diary for 2 weeks prior to starting
treatment. We expanded the usual panic monitoring
with additional ratings of panic-related concerns recommended by consensus conference experts (Shear and
Maser, 1994). The diary comprised daily and weekly
ratings of panic expectancy, ratings on how bad it would
be to experience a panic attack (expected aversiveness of
the attack), a daily rating of the highest fear of panic
during the day, and whether panic had actually occurred. The purposes of the study were: 1) to examine
the reliability and validity of these self-monitoring measures; 2) to determine whether assessment of panic is
improved by adding daily ratings of fear of panic; and 3)
to determine whether, as suggested by the consensus
conference experts, breaking down fear of panic into
two components—expectancy of panic and expected
aversiveness—increases the incremental validity of
panic assessment.
METHODS
SUBJECTS
The sample consisted of 37 patients (30 female, 7
male) suffering from panic disorder with at least moderate agoraphobic avoidance (PDA) and accepted for
participation in a clinical trial for their disorder.1 All
patients were diagnosed by a clinical psychology doctoral student trained in using the SCID for DSM-IV
(Spitzer et al., 1989). Patients’ mean age was 39.9
(SD = 9.2); their mean duration of complaints was 13.3
years (SD = 8.4).
The inclusion criterion was a primary diagnosis of
PDA of at least 1 year’s duration. No minimum number of panic attacks per week was required. Excluded
were applicants with a SCID-I diagnosis of present
substance dependence, current major depressive episode, or present or past psychosis; or a SCID-II diagnosis of paranoid, schizoid, schizotypal, antisocial, or
1
Other data on the same sample of patients are included in a
paper on the Beck Anxiety Inventory (de Beurs et al., 1997).
borderline personality disorder. Other comorbid diagnoses were acceptable unless they caused severe impairment in functioning according to SCID ratings. Also
excluded were patients who used >2 mg alprazolam a day
or equivalent dosages of other benzodiazepines, and those
not yet stablized on medication. Those on medication
(43% of the sample) were required to maintain a stable
dosage throughout their participation.
MEASURES
Panic diary. As previously described, the panic diaries were used for continuous self-monitoring of fullblown panic attacks. In addition, each morning the
patient rated the chance of having a panic attack during
the ensuing day according to an 11-point scale (0 = “I
will have no panic attack”; 10 = “I will definitely have a
panic attack”), as well as how bad it would be to have an
attack that day (0 = “Not bad at all”; 10 = “Extremely
bad”). These are the daily panic expectancy and expected aversiveness ratings, respectively. At the end of
the day, patients noted the number of panic attacks experienced that day (daily panic frequency) and retrospectively rated the highest level of fear they had
experienced that day about having a panic attack (0 =
“No fear at all”; 10 = “Extreme fear”). Finally, at the
end of each week of monitoring, the subjects rated the
chance of having a panic attack during the next week
and how bad that would be (weekly panic expectancy
and expected aversiveness ratings).
Self-report questionnaires included the Mobility
Inventory (MI) (Chambless et al., 1985), the Brief
Symptom Checklist (BSI) (Derogatis, 1975), the Agoraphobic Cognitions Questionnaire and the Body Sensations Questionnaire (ACQ and BSQ) (Chambless et
al., 1984), the Beck Anxiety Inventory (BAI) (Beck and
Steer, 1990), the Beck Depression Inventory (BDI)
(Beck and Steer, 1987), and the Panic Appraisal Inventory (PAI) (Telch et al., 1989). With the exception of
the PAI, all are widely used reliable and valid measures of their constructs.
The PAI is a relatively new measure designed to assess various aspects of panic disorder, especially cognitive features: anticipation of panic in circumscribed
situations, panic-related concerns, and self-efficacy in
coping with panic attacks in agoraphobic situations.
Telch et al. (1989) have reported good psychometric
properties. Test–retest reliability ranged from r = .81–
.89, and internal consistency ratings ranged from α =
.88 to α = .94). Data reported by Feske and de Beurs
provided support for the PAI’s concurrent validity
(Feske and de Beurs, 1997).
Interviewer’s ratings. The assessor rated the severity of the patient’s psychopathology following the
Panic Disorder Severity Scale (PDSS) (Shear et al.,
1998). Each item on this 7-item scale is scored on a
5-point scale, ranging from 0 to 4. Three items address panic specifically: panic frequency, distress during panic (panic severity), and anticipatory anxiety
(worry about future panic attacks). The other four
Research Article: Modified Panic Diary
items refer to agoraphobic fear and avoidance, interoceptive fear and avoidance, and level of impairment in vocational and social functioning due to the
disorder. Items can be used individually or can be
taken together to form one composite scale of severity of the patient’s condition. Shear and colleagues
have reported positive findings on the psychometric
properties of the PDSS. The PDSS items were demonstrated to form one factor with moderate internal
consistency (α = .65) and excellent inter-rater and
test–retest reliability (intraclass correlation coefficients of .87 and .88, respectively). Convergent and
divergent validity of the individual items and the
composite score were also generally supported.
PROCEDURE
Written informed consent was obtained from all
patients before starting the assessment procedure.
After the SCID, patients meeting entry criteria
were carefully instructed on the definition of panic
(Shear and Maser, 1994). The interviewer emphasized the sudden onset and limited duration of panic
to distinguish it from more chronic forms of high
anxiety. In addition, he described the distinction between full-blown panic attacks and limited symptom
episodes and instructed patients to record fullblown panic attacks only. Patients were asked to
record every panic attack immediately after its occurrence, to indicate which panic symptoms they experienced on a checklist, and to monitor their panic
expectancy and fear of panic each day for 2 weeks
prior to starting treatment. They received monitoring
materials and written instruction on the definition of
panic, including a list of the 13 panic attack symptoms
of the DSM-IV. The instructions also contained a detailed description of each variable to be recorded.
Patients monitored panic for 2 weeks prior to
starting treatment. After 1 week, the patient returned
to the clinic for an assessment session during which
the results of the first week of monitoring were reviewed and discussed, and any instructions the patient found confusing were reiterated and clarified.
The battery of self-report measures was administered
and, finally, the interviewer (a doctoral level clinical
psychologist with extensive experience with PDA)
rated the severity of panic disorder according to the
Panic Disorder Severity Scale.
135
RESULTS
DESCRIPTIVE DATA
The present analyses focus on pretreatment diary
data, collected during baseline. For most patients (n =
27, 73%), panic frequency ranged from 1–12 attacks
during the 2-week period. However, as is common for
agoraphobic patients, 9 patients (24%) reported no
panic during the same period. The data of one outlier,
who reported 35 attacks, were excluded. Daily scores
for panic expectancy, expected aversiveness, and fear
of panic were aggregated into weekly averages to induce the amount of data and increase reliability.
Descriptive analyses for the remaining 36 patients
revealed that, as is typical, the panic frequency data
had a highly peaked (kurtosis = 7.16) and positively
skewed distribution (skewness = 2.10), due to the large
number of subjects who reported no panic attacks
(31%) or only one panic attack (14%) in the first
week. All other diary variables had normal distributions. After square root transformation, both skewness
(0.14) and kurtosis (–0.58) of the panic frequency variable were acceptable for parametric analysis.
The mean scores of the first 2 weeks of monitoring
are presented in Table 1. Comparing the means of
weeks 1 and 2 gives an indication of the stability of the
measures. The correlations between week 1 and 2 data
provide information on short-term test–retest reliability. During baseline, panic frequency was quite reliable
but decreased to a small, but statistically significant degree. Daily aggregated ratings were both reliable and
stable, whereas weekly predictions were reliable but increased significantly from week 1 to week 2.
CONVERGENT AND DIVERGENT VALIDITY
Relationships among diary measures. To examine
whether the three new diary ratings measured the same
construct and to gauge their relationship to panic
frequency, a correlation matrix was constructed.
Presented in Table 2 are the correlations of the aggregated daily scores (in 1-week blocks) and the weekly
prediction scores, as well as the average value for daily
correlations. Aggregated scores should increase the reliability, and therefore the validity coefficients, of
single-item data such as these ratings. Indeed, this was
the case.
TABLE 1. Comparison of panic measures in week 1 and week 2
Week 1
Panic frequency
Fear of panic
Panic expectancy
Expected aversiveness
(transformed)
(aggregated)
(aggregated)
(next week)
(aggregated)
(next week)
Week 2
Mean
SD
Mean
SD
t(34)
P
Test–
retest r
1.24
4.25
4.00
6.50
5.12
6.17
1.01
2.22
1.92
2.34
1.88
2.05
1.00
4.45
4.20
5.60
5.28
5.63
0.88
2.72
2.26
2.29
2.20
2.16
2.26
–0.72
–0.66
3.44
–1.42
2.02
.03
.48
.51
.01
.16
.05
.78
.77
.84
.81
.91
.77
136
de Beurs et al.
TABLE 2. Correlation coefficients among panic measures
Fear of panic
Week 1:
Panic frequency
Fear of panic:
Panic expect.:
Week 2:
Panic frequency
Fear of panic:
Panic expect.:
Panic expectancy
Expected aversiveness
daily (r– )
aggregated
daily (r– )
aggregated
next week
daily (r– )
aggregated
next week
.40
.44**
.26
.59
.49**
.65**
.11
.46
.14
.17
daily
aggregated
daily
aggregated
next week
.67**
.53**
.51
.39*
.53**
.38
.48**
daily
aggregated
daily
aggregated
next week
.37
.72
.60**
.54**
.22
.65
.79**
.29
–.06
.74**
.55
.54**
.45**
*P < .05; **P < .01.
Panic frequency was moderately correlated with fear
of panic and panic expectancy, but not with expected
aversiveness, suggesting this last variable has a somewhat different character from the other two new
ratings. The pattern observed in week 1 was replicated in
week 2. At both week 1 and week 2, the new variables
(expectancy, aversiveness, and fear of panic) were all
strongly intercorrelated, but the correlations between
aversiveness and expectancy were lower than the correlations of fear of panic with each of the other two
variables. These differences, tested with procedures
suggested by Steiger (1980) for comparing dependent
correlations, were statistically significant (all T2(33) >
2.19; all P < .05) for all contrasts in weeks 1 and 2,
with one exception. The difference between the
aversiveness–expectancy correlation and the fear of
panic–aversiveness correlation for week 1 was in the
same direction as the others (.39 vs. .53, respectively),
but not statistically reliable, T2(33) = 1.16, P > .05.
Overall, these data again suggest that the aversiveness
and expectancy ratings are not simply two ways of
asking the same question.
Table 2 also includes correlations for the patient’s
predictions for the upcoming week. Once again, the
correlations of panic frequency with expected aversiveness were minimal. Correlations of expectancy and
aversiveness are roughly comparable to those of the
aggregated daily ratings.
Relationships between diary measures and
questionnaire and interviewer measures. Analyses
of convergent and divergent validity with questionnaire and interviewer measures relied on the diary
data from week 1 of monitoring, the week that corresponded to the time interval specified as the reference
point for completing the other-method measures. The
Beck Depression Inventory (BDI) was included as a
measure of divergent validity. Because demoralization
is common among panic patients, some correlations
between the BDI and panic measures were expected,
but these should not be as high as the convergent validity coefficients. In Table 3, key convergent validity
coefficients are presented in italics.
Convergent validity of the fear of panic rating was
assessed via correlations with the PAI Coping subscale
inquiring how confident patients are of their ability to
cope in agoraphobic situations or when they have a
panic attack. Following Telch et al. (1989), we reasoned that patients should be fearful of panic to the
degree that they believe they are unable to cope with
it. As expected, patients who rated themselves lower in
self-efficacy reported significantly higher fear of panic.
Further, as predicted, higher fear of panic ratings were
correlated with higher scores on the PAI scale on
which patients are asked to indicate the likelihood of
panic in various agoraphobic situations, and with
higher scores on the PDSS anticipatory anxiety item,
designed to assess worry about further occurrence of
panic. Contrary to expectation, the fear of panic rating
was not significantly correlated with the Body Sensations Questionnaire, which assesses fear of physical
symptoms of panic attacks, although a modest and
positive correlation (P < .07) was obtained. Divergent
validity is supported by the comparatively lower and
nonsignificant correlation with the BDI.
To examine convergent validity of the expectancy of
panic rating, we correlated it with two scales we predicted to be related: the PAI anticipatory panic scale
and the PDSS anticipatory anxiety item. Data supporting our predictions were statistically significant
only for patients’ predictions for the next week, although correlations for the daily aggregated ratings
tended to significance, both P < .10. Divergent validity
vis-à-vis the BDI was clear for both weekly and daily
aggregated ratings.
For convergent validity of the expected aversiveness
rating, the diary measure was correlated with the PAI
Research Article: Modified Panic Diary
137
TABLE 3. Correlations of continuous monitoring measures with self-report measures and PDSS itemsa
Panic expectancy
Measure
MI panic frequency
PDSS panic frequency
PAI coping
PAI anticip. panic
PDSS anticip. anxiety
BSQ
PAI concerns
PDSS panic distress
BDI
MI alone
BAI
BSI
PDSS composite
Panic frequency
.74**
.75**
–.14
.16
.09
.16
–.18
.41*
.21
–.11
.34*
.40*
.40*
Fear of panic
Expected aversiveness
Aggregated
Next week
Aggregated
Next week
.56**
.53**
–.26
.30
.28
.17
–.04
.28
.05
.31
.38*
.37*
.48**
.57**
.65**
–.24
.43**
.34*
.36*
.04
.41*
.12
.21
.54**
.46**
.60**
.25
.07
–.24
.34*
.18
.36*
.43*
–.03
.18
.33*
.42*
.48**
.28
.21
.17
–.02
.36*
.35*
.45**
.25
.20
.21
.22
.50**
.50**
.46**
.58**
.56**
–.40*
.38*
.45**
.31
.28
.26
.22
.33*
.52**
.47**
.55**
a
MI, Mobility Inventory; PDSS, Panic Disorder Severity Scale; PAI, Panic Appraisal Inventory; BSQ, Body Sensation Questionnaire; BAI, Beck Anxiety
Inventory; BDI, Beck Depression Inventory. Italicized correlations are predicted covergent validity coefficients.
*P < .05; **P < .01.
Concerns scale, on which the patient rates concerns
about negative consequences of attacks. Additionally,
we predicted that the aversiveness rating would be associated with higher scores on the BSQ, indicating
greater fear of the bodily sensations of panic. With
one exception, both predictions were supported for
daily aggregated as well as weekly data. Contrary to
prediction, we did not find that patients who thought
having a panic attack would be a very bad thing were
those who were rated as having more severe attacks on
the PDSS.
CONSTRUCT VALIDITY
To further examine the construct validity of the
panic diary measures, we explored the incremental validity of adding the extra ratings to panic frequency
for the measurement of important aspects of PDA
psychopathology, including agoraphobic avoidance,
generalized anxiety, overall severity of panic disorder,
and global psychological distress. Two questions were
addressed: 1) Will adding ratings of fear of panic improve the assessment of the given problem? 2) Does
dividing fear of panic into panic expectancy and expected aversiveness further improve assessment?
Four hierarchical multiple regression analyses were
performed to address these questions. First, we investigated whether fear of panic, panic expectancy, and
expected aversiveness ratings predicted additional variance, beyond that accounted for by panic frequency, in
scores on the Mobility Inventory (Avoidance Alone),
the Beck Anxiety Inventory, the General Severity Index
of the Brief Symptom Inventory, and the clinician-rated
PDSS composite rating. These criterion variables represent a range from those very specific to this PDA
population (avoidance) to a measure of general distress
(the BSI). In each equation followed by fear of panic,
expectancy of panic, and expected aversiveness (week 1
aggregated ratings for all variables). At each step, we
tested whether the next variable to enter would contribute to the predictive power of the equation to a statistically significant degree.
The simple correlations of predictors with the criterion variables are given in Table 3 to facilitate interpretation. Results of the hierarchical regression equations
are given in Table 4. The first column gives the multiple R2; the second column depicts the F value for testing whether any increase in explained variance is
statistically significant.
In every equation one or two of the new diary measures added to the prediction of PDA symptomatology.
TABLE 4. Hierarchical regression analyses for panic
measures as predictors of psychopathologya
Dependent variable
Avoidance (MI)
Predictor
Frequency of panic
+ Fear of panic
+ Expectancy of panic
+ Expected aversiveness
Anxiety (BAI)
Frequency of panic
+ Fear of panic
+ Expectancy of panic
+ Expected aversiveness
General psychopathology Frequency of panic
(BSI)
+ Fear of panic
+ Expectancy of panic
+ Expected aversiveness
Severity rating (PDSS
Frequency of panic
composite)
+ Fear of panic
+ Expectancy of panic
+ Expected aversiveness
a
R2
.01
.19
.23
.25
.12
.29
.29
.32
.16
.27
.27
.36
.16
.34
.35
.35
Finc
7.42*
1.71
0.69
7.98**
0.00
1.46
4.92*
0.00
4.37*
8.83*
0.45
0.00
MI, Mobility Inventory; BAI, Beck Anxiety Inventory; BSI, Brief
Symptom Inventory; PDSS, Panic Disorder Severity Scale.
*P < .05; **P < .01.
138
de Beurs et al.
Fear of panic, forced into the equation first, consistently added significantly to explanation of the variance. With one exception (the BSI), expected
frequency and aversiveness ratings did not add further to the equations. As seen in Table 3, this was
not necessarily because expected panic and
aversiveness failed to be related to the criterion variables. The zero-order correlations were consistently
significant for the BAI and almost uniformly so for
the PDSS composite; expectancy was as strongly related to avoidance as was fear of panic. Further, examination of the regression diagnostics indicated
that, although the three new diary measures are
intercorrelated, multicollinearity was not problematic. Hence, it is likely that expectancy and
aversiveness ratings fail to add significantly to the
prediction of PDA psychopathology because the predictive portion of their variance (captured with the
zero-order correlations) is the same portion that
covaries with fear of panic ratings, which had the advantage of being forced into the equations immediately after panic frequency.
Accordingly, we conducted additional analyses to
further test the possible advantages of decomposing
fear of panic into panic expectancy and expected
aversiveness while avoiding the bias in favor of the
fear of panic rating inherent in the hierarchical regression approach. We compared the predictive utility of fear of panic ratings to that of panic expectancy
and expected aversiveness ratings, used jointly, in accounting for variance in the residualized criterion
variables (controlling for panic frequency). The size
of the effect for expectancy and aversiveness did not
consistently exceed that for fear of panic alone. Even
on those occasions when using these two variables
did account for more of the variance than fear of
panic alone, the difference never approached significance; all T2 < 0.68, all P > .20. These results confirm
the conclusion drawn from the hierarchical regressions: Breaking down fear of panic into expectancy of
panic and expected aversiveness does not seem to improve the assessment of panic-related concerns.
DISCUSSION
We tested the reliability and validity of three new
ratings for a daily panic diary—fear of panic, expectancy
of panic, and expected aversiveness of panic—along with
the familiar measure of frequency of self-monitored
panic attacks. All new measures demonstrated good
short-term reliability whether we used daily ratings
aggregated over a 1-week interval, or (in the case of
expectancy and expected aversiveness) once-weekly predictions of the patient’s likely experience in the following week. Panic frequency was also reliable over the
2-week pretreatment monitoring interval.
Divergent validity for all measures, assessed against
the Beck Depression Inventory, was also consistently
good. Self-monitored panic frequency was highly con-
sistent with reports of panic on a questionnaire and to
the clinical interviewer. However, these convergent validity coefficients are likely to be somewhat inflated.
The very fact that patients had been self-monitoring is
likely to have colored their report of panic to the clinical interviewer and on the questionnaire, probably by
increasing the accuracy of their report.
Convergent validity of the new measures of panicrelated concerns was more uneven. The majority of
(although not all) tests were positive for fear of panic
and expected aversiveness ratings; but, where expectancy of panic was concerned, convergent validity was
only obtained for weekly predictions, not for daily ratings. Incremental validity was uniformly demonstrated
for the fear of panic rating. When fear of panic was
divided into expected occurrence of panic and expected
aversiveness of panic, these ratings, used jointly, were
equivalent to the fear of panic rating in incremental validity. However, they did not exceed the contribution
made by the 1-item fear of panic rating alone.
Because we found no evidence that the expectancy of
panic rating and the expected aversiveness rating added
to the prediction of PDA symptomatology already accomplished via frequency of panic and fear of panic
ratings, our findings do not suggest that splitting fear
of panic into two ratings of expected aversiveness and
expectancy of panic is necessary. Just as much can be
accomplished with one more economical, less burdensome fear of panic rating. In addition, convergent validity findings were stronger for the fear of panic rating
than the expectancy of panic rating, to which it was
highly correlated, making the former more psychometrically desirable than the latter. However, a cautionary note is required. All of our data concerned
pretest symptoms only. It remains possible that the two
separate ratings for components of fear of panic might
prove useful in research on the process of change in
treatment, or might demonstrate differential treatment
outcome for different approaches to treatment. For the
answer to this question, data from pharmacological and
cognitive–behavioral treatment trials are needed. Second, expectancy of panic is interesting in its own right.
There is a large body of literature suggesting that an
important feature of anxiety disorders in general and
panic disorder in particular is the sufferers’ tendency to
overpredict fear or panic (Rachman, 1994). Because
most of this research has been carried out in the laboratory, generalization of laboratory findings to naturally occurring panics in the patients’ environment
requires investigation. Incorporating panic expectancy
ratings in the continuous self-monitoring records
would provide the necessary data.
Another economy of measurement could be effected
by using weekly ratings for panic expectancy and expected aversiveness. On the whole, comparing the results obtained with daily vs. weekly measures indicates
that the weekly measures are equally reliable and valid.
Panic researchers are plagued by the difficulty in obtaining consistent self-monitoring records (Shear and
Research Article: Modified Panic Diary
Maser, 1994). Reducing demands on patients with
weekly rather than daily ratings might foster cooperation
with this onerous assessment approach. This point is
worth exploring in future research. For now, we caution
researchers not to throw out daily ratings on the basis of
these initial data. The quality of the weekly estimates
may have been increased by the very fact that patients
kept daily records of panic and anxiety and were, therefore, more apt to quantify their complaints accurately.
We conclude that, as advocated by the researchers
attending the consensus conference on panic assessment (Shear and Maser, 1994), adding a rating of fear
of panic to panic diaries is highly desirable. We suggest that our study be replicated in a sample of patients without extensive agoraphobic avoidance. In
studies conducted with questionnaire measures tapping the fear of panic construct, panic disorder patients with agoraphobia have demonstrated higher fear
of panic than less avoidant patients (e.g., Chambless
and Gracely, 1989; Cox et al., 1991). Thus, the incremental validity of fear of panic may be especially high
in an agoraphobic population.
Acknowledgments. This research was supported
by NIMH grant R21-MH 49851. We thank Maria
Belecanech and Marnita Floyd for serving as SCID
interviewers.
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