[The importance of limiting values of limiting values of acid-base equilibrium in the fetus in the indications for induced delivery].
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Experiences with patients with facial paralysis over the last 25 years and recent efforts to develop objective measures of paresis and synkinesis led us to three hypotheses: (a) dysfunction in certain regions of the face is more disturbing than that in others, (b) there are major psychosocial impacts of facial paralysis, and (c) the impact of facial paralysis is underestimated. An initial questionnaire of 10 open-ended items was submitted to 11 subjects stabilized after acoustic tumor resection. Responses were tabulated qualitatively, and frequency counts were made of responses. These results show that the region of the face that is most disturbing is the mouth; however, early in the time course of paralysis, the eye is most disturbing. Synkinesis above the eye is ultimately more disturbing than paresis in that region, and it may worsen. Major psychosocial impacts of paralysis appear common and underestimated. These pilot data qualitatively support the hypotheses.
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BACKGROUND: Depressed mood may either precede mobility limitation or follow from mobility limitation. OBJECTIVE: To compare mood status among people with manifest mobility limitation, those with preclinical mobility limitation and those without mobility limitation and investigate factors explaining the association between depressed mood and mobility limitation. DESIGN: Cross-sectional. SUBJECTS: 645 community-living 75- to 81-year-old people. METHODS: Depressed mood was assessed using the Centre for Epidemiologic Studies Depression Scale (CES-D, cut-off score 16); difficulty walking 500 m was assessed by self-report. Those reporting difficulty were categorised as having manifest mobility limitation. Those with no difficulty but reporting task modifications, such as reduced frequency of walking, were categorised as having preclinical mobility limitation. The association between depressed mood and mobility limitation was analysed using logistic regression analysis with gender, age, economic situation, the availability of a confidant, chronic conditions, and widespread pain as covariates. RESULTS: Depressed mood was found in 34% of subjects with manifest mobility limitation, in 26% of those with preclinical mobility limitation, and in 13% of those without mobility limitation. The unadjusted odds ratio for depressed mood was 3.43 (95% CI 2.04-5.76) among subjects with manifest mobility limitation and 2.38 (95% CI 1.52-3.73) among those with preclinical mobility limitation, compared to those without mobility limitation. Adjustment for covariates reduced the risks to 2.10 (95% CI 1.15-3.82) and 1.99 (95% CI 1.24-3.20), respectively. Widespread pain explained 28% of the increased risk of depressed mood among those with manifest mobility limitation. CONCLUSION: The dose-response relationship between depressed mood and mobility limitation suggests that both conditions may progress simultaneously and may share aetiology, at least in part. Pain may be an underlying factor in both depressed mood and mobility limitation.
PURPOSE: (1) To develop novel scaled bioequivalence (BE) limits with levelling-off properties based solely on variability considerations and (2) to evaluate their performance in comparison to the classic unscaled BE limits 0.80-1.25, the expanded BE limits 0.75-1.33 and the recently proposed Geometric Mean Ratio (GMR)-dependent scaled BE limits BELscW (Karalis et al., Eur. J. Pharm. Sci., 26:54-61, 2005). MATERIALS AND METHODS: Two model functions were used to ensure the gradual change of the BE limits from a starting value towards a predefined plateau value. Plots of the new BE limits and extreme GMR values ensuring BE as a function of the coefficient of variation (CV) were constructed. Two-period crossover BE studies with 12, 24, or 36 subjects were simulated assuming CV values from 10 to 60%. Power curves were constructed by recording the percentage of accepted BE studies as the true GMR was raised from 1.00 to 1.50. The percentage of the true GMR within the simulated BE limits vs. true GMR was used to evaluate the estimation accuracy of the scaled methods. RESULTS: Depending on the parameters' values of the model functions, the scaled BE limits exhibit different performance. Four new scaled BE limits, showing favourable performance for the evaluation of average BE are presented. At low variability levels two of the novel BE limits show similar performance to the 0.80-1.25 criterion, while the other two (as expected from their design) appear to be less permissive. At high CV values (30, 40%) all new BE limits exhibit much higher statistical power than the 0.80-1.25 criterion. They show almost identical behavior with the expanded 0.75-1.33 limits and appear to be less permissive than BELscW. Finally, the percentage of the true GMR within the simulated BE limits vs. true GMR shows a sharp decline. Due to the absence of the GMR factor in the model functions a more accurate estimation of the new scaled BE limits, compared to BELscW, is observed. CONCLUSIONS: The new scaled BE limits appear to be highly effective at all levels of variation investigated and present satisfactory estimation accuracy.
OBJECTIVES: The goals of this study were to determine the probability of successful defibrillation at the upper limit of vulnerability and to evaluate a minimal safety margin for implantable cardioverter-defibrillator first shocks based solely on the upper limit of vulnerability. BACKGROUND: The upper limit of vulnerability is the strength at or above which ventricular fibrillation is not induced when a stimulus is delivered during the vulnerable phase of the cardiac cycle. It has been proposed as an estimate of defibrillation efficacy because it correlates with the defibrillation threshold and can be determined with a single episode of fibrillation. METHODS: We studied 40 patients prospectively at implantation of transvenous cardioverter-defibrillators. Defibrillation threshold was defined as the weakest biphasic shock that defibrillated after 10 s of ventricular fibrillation. The upper limit of vulnerability was defined as the weakest biphasic shock that did not induce ventricular fibrillation when given at 0, 20 and 40 ms before the peak of the T wave in ventricular paced rhythm at cycle length 500 ms. After determination of the upper limit of vulnerability and defibrillation threshold, patients underwent six additional fibrillation-defibrillation episodes. The strength of five of the defibrillation shocks was equal to the upper limit of vulnerability; the strength of one of the six shocks was randomly selected to be equal to the upper limit of vulnerability plus 3 J. The implantable cardioverter-defibrillator was tested at the upper limit of vulnerability plus 3 J in 28 patients. RESULTS: The defibrillation threshold was 8.8 +/- 5.0 J (mean +/- SD), and upper limit of vulnerability was 11.3 +/- 4.6 J; the defibrillation threshold and upper limit of vulnerability were highly correlated (r = 0.89, p < 0.001). The success rate for the 200 defibrillation shocks with strength equal to the upper limit of vulnerability was 90% (95% confidence intervals based on proportion of successes in 40 patients: 86% to 94%). All five defibrillation test shocks at the upper limit of vulnerability were successful in 24 patients (60%); four of five were successful in 12 patients (30%); and three of five were successful in 4 patients (10%). All 40 test shocks and 28 implantable cardioverter-defibrillator shocks with a strength equal to the upper limit of vulnerability plus 3 J were successful. CONCLUSIONS: The upper limit of vulnerability is a good estimator of the shock strength associated with 90% probability of successful defibrillation (DFT90). A strength of 3 J above the upper limit of vulnerability is a good estimate of the minimal acute safety margin for implantable cardioverter-defibrillator first shocks.
OBJECTIVES: This paper (a) creates and validates measures for population survey data to assess functional limitation in mobility, self-care, communication, and learning ability for school-age American children; (b) calculates rates of functional limitation using these measures, and provides population estimates of the number of children with limitations; and (c) examines these limitations as a function of socioeconomic factors. METHOD: The study is based on data for children aged 5-17 collected in the 1994 National Health Interview Survey on Disability. Ordinal values are assigned to survey items in the four functional areas and analyzed to produce scales of high reliability. These measures are used to identify within a 95% confidence interval the number of children with these limitations. Ordered logistic regression models measure the effects of functional limitations on disability and societal limitation. Socioeconomic differences are measured with an ordered logistic regression model that predicts severity and comorbidity. RESULTS: Limitations in learning ability (10.6%) and communication (5.5%) are the most common, with mobility (1.3%) and self-care (0.9%) occurring less often. Six percent of children have one serious functional limitation and 2.0% have two or more serious functional limitations. This corresponds to 4.0 million school-age American children with serious functional limitations. Functional limitation is strongly linked to socioeconomic disadvantage and to residence in single-mother households. CONCLUSIONS: Future population research should use multiple-item scales for four distinct areas of functional limitation, and a summary that takes into account both severity and comorbidity. The improved estimates of the number of school-age children with functional limitation in this paper may help contribute to a more informed scientific and policy discussion of functional limitation and disability among American school-age children. Future research on the disability process among children must consider the role of socioeconomic disadvantage and family structure.