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1 left main CAD from 77% (pretest) to 95-100% (posttest).
2 asis from 15% to 44% (pretest) to 3% to 18% (posttest).
3 a different intraoperative crisis scenario (posttest).
4 c patients (P < 0.0001; analysis of variance posttest).
5 All visitors were offered a posttest.
6 a pretest and again, 2 weeks later, during a posttest.
7 - and between-group differences from pre- to posttest.
8 ap or in striatal activation from pretest to posttest.
9 task, and crowding ratios were reduced after posttest.
10 nswer, was chosen by >20% of students on the posttest.
11 rained residents also took a written pre and posttest.
12 sical function were assessed at baseline and posttest.
13 ng during the 8-10 d between the pretest and posttest.
14 Fellows' knowledge was assessed by pre- and posttest.
15 Six fellows completed both pre- and posttests.
16 dards and deviants at both early and delayed posttests.
18 we examined pretest (before instruction) and posttest (after instruction) responses from 751 students
20 aining and the transfer task from pretest to posttest and an increase in striatal activation in both
21 ness significantly decreased from pretest to posttest and follow-up after recall+EMs relative to the
23 ROP tutorial, ROP educational chapters, and posttest), and 29 of 58 trainees (50%) were randomized t
24 left main CAD from 23% (pretest) to 65-100% (posttest), and NI values <10 increased the probability o
25 created using clinical cases (20 pretest, 20 posttest, and 25 training chapter-based) developed from
29 es increased from the 10-item pretest to the posttest by 3.1 items for measles, 3.8 for influenza, 1.
31 AST tended to have larger increases in PA at posttest compared with participants who received health
32 cored 100% on first and second trials of the posttest, compared to those receiving the routine proced
37 ents, we tested listeners on a pretest and a posttest consisting of auditory relative-timing conditio
39 nducted in 2012 and had a randomized pretest-posttest controlled design with a 10-week follow-up.
40 icts, we enrolled 98 in a randomized pretest-posttest controlled experiment starting August 15, 2010,
45 veloping 6-y-olds in a 3-mo pretest-training-posttest design that was ecologically deployed (at schoo
50 t values for E=8.7 [3.0] and 5.4 [2.8]; mean posttest difference between conditions=3.4; P<.001; 95%
52 pated in a cross-sectionally sampled pretest-posttest evaluation of brochures, posters, and messages
53 e measure was mean participant scores at the posttest evaluation, which was conducted 4 months after
54 ecreased significantly (P<0.05) from pre- to posttest for 7 of 12 foods (trained group) by both calcu
55 ele-education system performed better on the posttest for accurately diagnosing plus disease (67% vs.
58 uding judicious genetic testing, pretest and posttest genetic counseling, interpretation and applicat
61 m]; 95% CI, 82-86 to 74 bpm; 95% CI, 72-76), posttest HR (mean, 128 bpm; 95% CI, 125-131 to 113 bpm;
62 ght in meters squared), and surgical center (posttest HR and HR difference were further adjusted for
64 test HR, and HR difference (resting HR minus posttest HR) were measured and musculoskeletal pain conc
65 mpletion, resting heart rate (HR), immediate posttest HR, and HR difference (resting HR minus posttes
68 itude of the P3 component to deviants across posttests, indicating a long-lasting effect of discrimin
72 ed to similar and significant changes in the posttest likelihood of cancer for both dense and fatty b
73 to 0.99), which, when present, increases the posttest likelihood of EAS to 74%, assuming a pretest pr
76 met or exceeded the minimum passing score at posttest: mean (internal jugular) = 93.9%, SD = 10.2; me
78 posttest only (n = 10), single-group pretest/posttest (n = 2), nonrandomized 2-group (n = 13), and ra
79 patient interventional (n = 13), pretest and posttest (n = 9), randomized clinical trials (n = 9), an
80 gns included single-group cross-sectional or posttest only (n = 10), single-group pretest/posttest (n
82 TT versus exercise MPI yields similar 2-year posttest outcomes while providing significant diagnostic
84 mance significantly improved from pretest to posttest (P = 0.008) regardless of the type of debriefin
85 sed from 85.1% to 87.0% overall (pretest vs. posttest; P<0.001) and from 80.6% to 82.0% for teenagers
88 sts used and it is recommended they estimate posttest probabilities according to likelihood ratios as
90 ange an individual's pretest disease odds to posttest probabilities and can confirm vCJD infection.
93 Use of functional MR increased the final posttest probabilities of hemispheric language dominance
94 e of functional MR increases importantly the posttest probabilities of hemispheric language dominance
95 rst-case-scenario (pretest probability, 50%) posttest probabilities were 94% and 13% for positive and
98 inance or ambidexterity, there was very high posttest probability (>or=95%) of a correlation between
99 dless of hand dominance, there was very high posttest probability (>or=96%) of a correlation between
100 opulation with ambidexterity, there was high posttest probability (80%-87%) of correlations between f
101 t-handed epilepsy population, there was high posttest probability (80%-97%) of a correlation between
102 handed nonepileptic subjects, there was high posttest probability (81%-83%) of a correlation between
103 s in peripheral blood failed to increase the posttest probability above 90% in this setting of Campyl
107 nhanced MR imaging significantly affects the posttest probability of deep myometrial invasion in pati
108 mogram was provided to assist calculation of posttest probability of disease from the calculated like
109 rinalysis are not able to reliably lower the posttest probability of disease to a level where a UTI c
110 ratios, which were analyzed to determine the posttest probability of language dominance by using func
111 ng out Campylobacter infection, defined as a posttest probability of less than 10%, was similarly obs
112 y showed only moderate increases in positive posttest probability of lymph node metastasis for all me
117 e evaluated to determine their impact on the posttest probability, defined as the likelihood of a dia
119 pecificity calculations from the pretest and posttest results of the educational intervention group v
122 .5 minutes), and sleep duration baseline and posttest scores for C=5.8 [1.1] and 6.0 [1.0]; for E=6.0
123 single imputation were used to estimate the posttest scores of patients who left treatment before co
124 of 1.06 (95% CI, 0.81-1.31) indicating that posttest scores were approximately 1 SD above pretest sc
125 training regimen, which was followed by two posttest sessions, separated by another week without tra
127 Data are presented from a 1-group pretest-posttest study examining the role of extensive counselin
130 mbined (symptoms, self-harm, and suicide) at posttest, the investigated psychotherapies were moderate
131 nd of potentially failing to determine which posttest therapeutic approach optimizes treatment benefi
133 p quality, sleep-onset latency (baseline and posttest values for C=26.1 [20.0] and 23.8 [15.3]; for E
134 for C=8.93 [3.1] and 8.8 [2.6]; baseline and posttest values for E=8.7 [3.0] and 5.4 [2.8]; mean post
135 global sleep score at 16 weeks (baseline and posttest values in mean [SD] for C=8.93 [3.1] and 8.8 [2
136 + WT showed greater improvements on pretest-posttest variables of executive function, working memory
139 Average knowledge scores for pretest and posttest were 3.32 and 5.88, respectively (maximum 10).
141 res between the initial pretest and the last posttest with performance increments following both expo
142 intervention group had better results at the posttest, with a mean (SD) score (out of a possible 160.
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