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Biomedical subjects

C W Ahn

Publications and source records attributed to C W Ahn.

28 records · Page 2Linked to original sources
PubMed1999

The validity of random urine specimen albumin measurement as a screening test for diabetic nephropathy.

To assess the validity of urine albumin concentration (UAC) and the urine albumin:creatine ratio (UACR) in a random urine specimen (RUS) for screening diabetic nephropathy in Korea, a total of 105 ambulatory diabetes mellitus patients (male:female, 52:53), ages 40-75 years (median 59 years) collected 105 RUSs after completing a timed 24 hour urine collection. Albumin was measured by immunonephelometry. According to the timed urinary albumin excretion rate (UAER) measured in the 24 hour collection (criterion standard), samples were classified normoalbuminuric (UAER < 20 micrograms/min; n = 50), microalbuminuric (UAER 20-200 micrograms/min; n = 30), and macroalbuminuric (UAER > 200 micrograms/min; n = 25). The receiver operating characteristics (ROC) curve of UAC and UACR in a RUS for screening of microalbuminuria (normo- and microalbuminuric samples; n = 80) and macroalbuminuria (micro- and macroalbuminuric samples; n = 55) were plotted. Pearson's coefficients of correlation of 24 hour UAER vs. UAC and UACR were 0.81 and 0.75, respectively (P < 0.001). The point of intersection with a 100%-to-100% diagonal for microalbuminuria were as follows: 31.0 mg/l for UAC and 32.5 mg/g for UACR; for macroalbuminuria 181 mg/l for UAC and 287.3 mg/g for UACR. The sensitivity and specificity of the cut-off points for microalbuminuria were 77% and 82% for UAC and 77% and 92% for UACR. The sensitivity and specificity of the cut-off points for macroalbuminuria were 84% and 90% for UAC and 88% and 90% for UACR. In present study, no difference was observed when comparing the performance of UAC and UACR based on a statistical comparison by McNemar test. The repeated measurements of UAC and UACR in the same individual were statistically similar and were correlated with each other. Based on these results, albumin measurements (UAC and UACR) in a RUS were considered as a valid test for screening diabetic nephropathy.

Adult↗
PubMed1997

Pharmacokinetics and toxicity of 120-hour continuous-infusion hydroxyurea in patients with advanced solid tumors.

A group of 18 patients with advanced cancer were entered on a phase I study of a 120-h continuous intravenous infusion of hydroxyurea. The dose of hydroxyurea was escalated in cohorts of patients from 1 to 2 to 3.2 g/ m2 per day. The primary dose-limiting toxicity was neutropenia, often accompanied by leukopenia, thrombocytopenia and generalized skin rash. Prophylactic treatment of patients with dexamethasone and diphenhydramine hydrochloride prevented the skin rash, but not the hematopoietic toxicities. The pharmacokinetics of hydroxyurea were studied in all patients. The steady-state concentrations of hydroxyurea were linearly correlated with the dose (R2 = 0.71, n = 18, P < 0.0001). The mean +/- SE concentrations were 93 +/- 16, 230 +/- 6 and 302 +/- 27 microM at 1, 2 and 3.2 g/m2 per day, respectively. The mean +/- SE renal and nonrenal clearances of hydroxyurea were 2.14 +/- 0.18 and 3.39 +/- 0.28 l/h per m2 (n = 16), neither of which correlated with the dose. The concentration of hydroxyurea in plasma decayed monoexponentially with a mean +/- SE half-life of 3.25 +/- 0.18 h (n = 17). The steady-state concentration of hydroxyurea was > 200 microM in all nine patients treated at 2 g/m2 per day, a dose which was well tolerated for 5 days. We recommend this dose for phase II trials in combination with other antineoplastic agents.

Adult↗
PubMed1996

Expression of bcl-2 by breast cancer: a possible diagnostic application.

Expression of bcl-2 is most commonly associated with the t(14;18) translocation present in most folicular lymphomas (1). More recently, bcl-2 oncoprotein has been identified in normal tissues and in nonhematologic malignancies. In this study, we investigate the use of bcl-2 as a marker to distinguish metastatic breast carcinoma from primary lung and gastric cancers, and we evaluate the role of bcl-2 as an independent prognostic factor in breast carcinoma and its relationship to other breast cancer markers. bcl-2 immunostains were done on 371 adenocarcinomas of the breast, lung, and stomach. Additionally, 231 samples of metastases from patients with breast or gastric cancer were evaluated for bcl-2 expression. All breast cancer tissue samples had immunohistochemical data on expression of estrogen and progesterone receptors, p53, neu/cerb2, and MIB-1. A large proportion (79.3%) of invasive breast carcinomas expressed bcl-2, whereas only 5.6% and 8.3% of pulmonary and gastric carcinomas did. Moreover, staining was moderate to intense in 70.2% of the breast cancers, compared with only one specimen of lung carcinoma (1.9%) and gastric carcinoma (0.9%) that showed moderate staining. There was agreement of bcl-2 expression between primary and metastatic sites in all specimens except one. Expression of bcl-2 in breast adenocarcinomas was significantly associated with hormone receptor positivity and low histologic grade. Nonetheless, 20.6% of bcl-2-positive specimens were estrogen receptor negative and 24.2% of bcl-2-positive specimens were progesterone receptor negative. Neither the presence nor the absence of bcl-2 expression significantly predicted disease-free survival or overall survival in patients with breast cancer. We conclude that adenocarcinomas with intense bcl-2 staining are more likely to be of breast than of pulmonary or gastric origin. We recommend the addition of bcl-2 to a panel of antibodies (estrogen receptor, GCDFP-15, and S100) that might contribute to the identification of a larger proportion of metastatic breast carcinomas, because almost one-half of the estrogen-receptor negative cancers were bcl-2 positive.

Adenocarcinoma↗
PubMed1993

Prognostic significance of immunohistochemical analysis of cathepsin D in low-stage breast cancer.

BACKGROUND: Cathepsin D is an estrogen-regulated lysosomal protease that may be overexpressed in breast cancer. Several studies based on biochemical analysis of tumor cytosol have shown that high levels of cathepsin D are associated with poor outcome in patients with breast cancer. In contrast, a few immunohistochemical studies have shown that cathepsin D positivity in breast cancer cells indicates a favorable prognostic outcome or is of no prognostic significance. METHODS: Because of the current controversy, the authors studied, using immunohistochemistry, the distribution (0 to 3) and intensity (0 to 3) of cathepsin D in Stage I and II infiltrating ductal carcinoma of the breast from 245 patients treated at the City of Hope National Medical Center, Duarte, California, from 1970 to 1986. A commercially available rabbit antiserum to purified human cathepsin D and the standard avidin-biotin complex method were used. Statistical analysis was based on a combined low (0 or 2) or high (3 to 6) score. RESULTS: A high cathepsin D score was associated with Stage II disease (P = 0.007), positive lymph nodes (P = 0.019), high nuclear grade (P = 0.005), and c-erbB-2 oncogene amplification (P = 0.013). Cathepsin D positivity was not an independent prognostic indicator of disease-free survival (DFS) or overall survival (OS). In a subgroup analysis, the presence of cathepsin D had only a modest association with predicting a shorter DFS in patients with negative lymph nodes (P = 0.072) or positive progesterone receptors (PR) (P = 0.086). CONCLUSIONS: Immunohistochemical analysis of cathepsin D, with the antiserum used in this study, is not an independent predictor of outcome in patients with breast cancer because of its strong associations with several well-established prognostic indicators.

Adult↗
PubMed1992

Pharmacokinetics and toxicity of continuous infusion (6S)-folinic acid and bolus 5-fluorouracil in patients with advanced cancer.

Twenty-seven patients with advanced cancer were entered in a phase I study of bolus i.v. 5-fluorouracil at a dose of 370 mg/m2/day for 5 days combined with a continuous i.v. infusion of (6S)-folinic acid for 5.5 days, starting 24 h in advance of the first 5-fluorouracil dose. The dose of (6S)-folinic acid was escalated in cohorts of patients from 250 mg/m2/day to a maximum of 1000 mg/m2/day. The pharmacokinetics of (6S)-folinic acid were studied in the 3 patients given 250 mg/m2/day and in 6 patients given 1000 mg/m2/day. The mean steady-state plasma concentrations of (6S)-folinic acid and its principal metabolite (6S)-5-methyltetrahydrofolate at the 250 mg/m2/day dose were 2.7 and 5.1 microM, respectively. Both concentrations were comparable to the concentrations produced when (6S)-folinic acid was administered as half of a (6R,S)-folinic acid mixture (E. M. Newman et al., Cancer Res., 49:5755-5760, 1989). At the 1000 mg/m2/day dose of (6S)-folinic acid, the concentration of (6S)-folinic acid was 15.3 microM, more than the 4-fold increase predicted by linear pharmacokinetics, while the concentration of (6S)-5-methyltetrahydrofolate was only 16.5 microM. The change in the ratio of the parent compound to its metabolite was accounted for by a decrease in the nonrenal clearance of (6S)-folinic acid, probably indicating saturation of its metabolism. The toxicities observed in this phase I trial, including stomatitis, diarrhea, neutropenia, and anemia, did not differ in nature or severity from those produced by 5-fluorouracil and (6R,S)-folinic acid when administered on the same schedule. Finally, the degree of toxicity did not appear to depend on the dose of (6S)-folinic acid over the range of doses tested.

Adult↗
PubMed1990

DSM III as a systemic culture pattern: studying intracultural variation among psychiatrists.

DSM III is viewed as embodying a pool of information pertaining to a systemic culture pattern of psychiatry and attempts are made to describe how psychiatrists understand and apply it using ideas from cognitive anthropology. Each of seven psychiatrists evaluated a group of patients in an intake setting. Seven broad categories of Axis I diagnoses were formed and the frequencies with which psychiatrists used these categories were computed. In addition, twelve arithmetical measures pertaining to the five axes of DSM III and a current functioning axis and the decision regarding disposition were also computed. Using these dependent variables, the study analyzes the similarities and differences among psychiatrists in the way they formulate intake evaluations. Psychiatrists' selections of Axis I diagnoses were highly intercorrelated but they differed greatly among themselves in the way they coded many of the axes of DSM III. Group correlations among diagnostic measures indicated a patterning among diagnostic measures and the nature of this patterning is discussed. Each psychiatrists' set of correlations among the twelve diagnostic measures was itself correlated with that of others and this showed a very high level of interpsychiatrist agreement. Deductions drawn from the cultural consensus model suggest that psychiatrists share an underlying 'grammar' that references the pool of information pertaining to DSM III.

Cultural Characteristics↗
PubMed1989

PROPOV-K: a FORTRAN program for computing a kappa coefficient using a proportional overlap procedure.

The computer program PROPOV-K allows the computation of an unweighted kappa coefficient for expressing interrater agreement in the general case in which multiple raters (not necessarily fixed in number) formulate a variable number of multiple diagnoses for each subject. PROPOV-K assesses agreement among lists of multiple diagnoses composed of nonordered categories. PROPOV-K calculates a kappa coefficient on the basis of estimating proportion of agreement between two diagnostic formulations as the ratio of the number of agreements between specific categories over the number of different specific categories mentioned in the two diagnostic lists. When multiple raters formulate a variable number of multiple diagnoses for each subject, the use of a kappa coefficient has been limited to researchers since there are no generally available computer programs. The purpose of this paper is to present a FORTRAN computer program allowing the computation of a kappa coefficient for the case mentioned above and to illustrate its use with examples respectively involving multiple psychiatric and multiple physical diagnoses.

Algorithms↗
PubMedDate not supplied

Explaining diagnostic complexity in an intake setting.

A one patient-one illness paradigm is implicit in the history and theory of psychiatry, and in basic research. Yet, in clinical practice and treatment populations in general, more than one diagnosis per patient is frequently encountered. How clinicians formulate comorbidity by means of DSM-III has rarely been investigated. In this study, the ideas of clinical condition and that of its diagnostic complexity are used to analyze descriptive features of a large number of patients seen in an intake setting. Axis I of DSM-III is used to measure diagnostic complexity. Complexity is analyzed in relation to demographic variables, to ratings entered in the remaining axes of DSM-III formulations, to symptom levels of patients, and to decisions involving disposition. Results indicate that analysis of diagnostic complexity by means of DSM-III yields a definable structure and that it can be related meaningfully to clinical factors. The idea of information uncertainty in diagnosis, i.e., the opacity versus transparency of a clinical condition, is also used to explain results. The ideas introduced and studied are shown to have value for social psychiatric research.

Adaptation, Psychological↗
PubMedDate not supplied

Nonparametric mixture logistic regression models for clinical disposition.

Psychiatric hospitalization is one of the most important decisions in the care of patients. This is attributed to the complexity and intensity of treatment and isolation of patients from the family and community into a typically highly controlled and supervised setting. Logistic regression models are fitted to assess the relationship between DSM-III axes and psychiatric hospitalization decisions. Since the apparent error rate tends to underestimate the true error rate, the estimate for the downward bias of the apparent error was computed. A generalization of the logistic regression model is fitted where the intercept is assumed to be a random parameter.

Adolescent↗