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The purpose of this study was to search for chromosomal susceptibility loci for comitant strabismus. Genomic DNA was isolated from 10mL blood taken from each member of 30 nuclear families in which 2 or more siblings are affected by either esotropia or exotropia. A genome-wide search was performed with amplification by polymerase chain reaction of 400 markers in microsatellite regions with approximately 10 cM resolution. For each locus, non-parametric affected sib-pair analysis and non-parametric linkage analysis for multiple pedigrees (Genehunter software, http://linkage.rockefeller.edu/soft/) were used to calculate multipoint lod scores and non-parametric linkage (NPL) scores, respectively. In sib-pair analysis, lod scores showed basically flat lines with several peaks of 0.25 on all chromosomes. In non-parametric linkage analysis for multiple pedigrees, NPL scores showed one peak as high as 1.34 on chromosomes 1, 2, 4, 7, 10, 15, and 16, while 2 such peaks were found on chromosomes 3, 9, 11, 12, 18, and 20. Non-parametric linkage analysis for multiple pedigrees of 30 families with comitant strabismus suggested a number of chromosomal susceptibility loci. Our ongoing study involving a larger number of families will refine the accuracy of statistical analysis to pinpoint susceptibility loci for comitant strabismus.</P>

This study was conducted to determine the gestational age-related reference range of the preload index [peak velocity during atrial contraction (A)/peak velocity during ventricular systole (S)] for the inferior vena cava (IVC), the right hepatic vein, the middle hepatic vein and the left hepatic vein. The slope and the intercept of the regression line for each preload index were compared among the 4 veins using analysis of covariance. Doppler measurements were obtained for the 4 veins of 316 normal fetuses at 22-40 weeks of gestation. A and S values were measured from the recorded flow velocity waveform of each vein and the A/S ratio was calculated as the preload index. The regression lines for the preload index of the 4 veins decreased gradually throughout gestation. Analysis of covariance revealed no significant differences in the slopes of the regression lines for the 4 veins. However, the intercepts of the regression lines for all hepatic veins were significantly higher than that of the regression line for the IVC (P<0.0001), with the difference ranging from 0.024 to 0.033. There were no significant differences among the intercepts of the regression lines for different hepatic veins. We concluded that the relationship between the preload index and the duration of gestation was statistically similar for all hepatic veins, and strongly resembled that for the IVC.

Allele and genotype frequencies for 15 short tandem repeat (STR) polymorphisms--D3S1358, TH01, D21S11, D18S51, Penta E, D5S818, D13S317, D7S820, D16S539, CSF1PO, Penta D, vWA, D8S1179, TPOX and FGA--in a Japanese population were estimated. No deviations of the observed allele frequency from Hardy-Weinberg equilibrium expectations were found for any of the systems studied. Between 2 new pentanucleotide STR loci, Penta E and Penta D, for which there is only limited data regarding the allelic distribution in Japanese, the Penta E locus was found to be highly polymorphic and exhibited a tri- or tetra-modal distribution pattern having allelic peaks with 5, 11, 15 and 20 repeats. The distribution was significantly different from that of the other ethnic groups. Statistical parameters of forensic importance, the power of discrimination (PD), observed and expected heterozygosity values (H), polymorphism information content (PIC), power of discrimination (PD), matching probability (pM), power of exclusion (PE), and typical paternity index (PI), were calculated for the loci. These parameters indicated the usefulness of the loci in forensic personal identification and paternity testing among Japanese. The systems Penta E, FGA, D18S51 and D8S1179 were the most informative. This method was successfully applied to forensic personal identification and paternity testing among Japanese, thereby confirming its efficacy for forensic practice.

Chemical shift MRI is widely used for identifying adenomas, but it is not a perfect method. We determined whether combined dynamic MRI methods can lead to improved diagnostic accuracy. Fifty-seven adrenal masses were examined by chemical shift and dynamic MR imaging using 2 MR systems. The masses included 38 adenomas and 19 non-adenomas. In chemical shift MRI studies, the signal intensity index (SI) was calculated, and the lesions classified into 5 types in the dynamic MRI studies. Of the 38 adenomas studied, 37 had an SI greater than 0. In the dynamic MRI, 34 of 38 adenomas showed a benign pattern (type 1). If the SI for the adenomas in the chemical shift MRI was considered to be greater than 0, the positive predictive value was 0.9, and the negative predictive value was 0.94 and kappa = 0.79. If type 1 was considered to indicate adenomas in the dynamic MRI, the corresponding values were 0.94, 0.81 and kappa = 0.77 respectively. The results obtained when the 2 methods were combined were 1, 0.95 and kappa = 0.96 respectively. The chemical shift MRI was found to be useful for identifying adenomas in most cases. If the adrenal mass had a low SI (0 < SI < 5), dynamic MRI was also found to be helpful for making a differential diagnosis.

For the purpose of forecasting the prevalence ofJapanese encephalitis in Japan, we tried to find out the correlation of factors between median and mode dates of epidemic time curve of prevalence on one hand, and average atmospheric temperatures of prefectures in June and July (T6,7 in short) (X¹), the time when HI reaction of swine became positive to the degree of 50 per cent (D. pos. swine in short) (X²), the latitude (x³) and longitude (x4) in respective prefectures (in 1965 and 1967). On the other we also estimated the median and mode dates of this epidemic curve of the prevalence in 1968 and 1969, from the regression equation of one variable and multiple regression equation from the above factors using an electronic computer. The usefulness of adding factors concerned with mosquitoes to the above four factors is proven by the accuracy of estimation. And the following results were obtained. 1) Phenomenally speaking, the prevalence of Japanese encephalitis follows the principle of "advancing of prevalence towards the north and east" and essentially speaking, it depends upon high atmospheric temperature and the outbreak of many hazardous mosquitoes by the high atmospheric temperature. 2) To estimate median date (y) and mode rate (z) of the epidemic time curve of the prevalence, we can use the next equations; The regression equations to estimate y and z from T 6,7(X) are as follows. y = - 3. 75X¹ + 144.47 σ = 12.4.·. [1] z = - 3. 80X¹ + 157 .26 σ = 14.9.. · [1]' The regression equation from D. pos. swine (X²) are as follows. y = 0. 68X² + 31. 82 σ = 9.2· .. [2] z=0. 76X² +40. 71 σ= 12.0 .. · [2]' The multiple regression equation from T6 ,7 and D. pos. swme are as follows. y = -1. 07X¹ +0 .62x² +59. 37 σ= 9.7 ... [3] z= -0. 79x¹ +0. 71x² +61.02 σ= 12.0· .. [3]' The multiple regression equations from T 6•7, D. pos. swine, latitude and longitude are as follows Y= -1.01x¹ +0.58x² -0.26x³+0 .37x4 + 18.50 σ= 9.8･･･ [4] z = -0. 32x¹ +0. 52x² +2 .05x³ +0 .54x4 -87. 81 σ= 11.8 [4]' 3) We Obtained the estimated value of median date in 17 prefectures in Kyushu, Chugoku, Shikoku, Kinki and Kanto provinces in 1968 and in 13 prefectures in 1969 from [l] or [2] or [3] or [4] equation. Nine prefectures out of 17 by [l], 12 prefectures by [2], 13 by [3J and [4] in 1968. [4] could be estimated with about 10 days error or less. And in 1969, 9 out of 13 by [3] and 7 out of 13 by [4] could be accurately esti· mated. The estimation by the multiple regression equation using many factors is most useful for the calculation. 4) The time when the number of patients increases at maximum can be pointed out by the lower limit of prediction region obtained from data in each prefecture. And the lower limit was the estimated median value minus about 20 days by [1] and about 16 days by [2] or [3] or [4] under the next condition; α = 0. 1, N= 75. 5) The mode dates in 17 prefectures out of 19 were estimated by [1]', [2]', [3]' and [4]'. 12 prefectures out of 17 by [1]', 7 by [2]', 10 by [3]' and 13 by [4]' could be estimated with about 12 days error or less in 1968 and 9 out of 13 was correctly estimated by [3]' and [4]' in 1969. The estimation by the regression line of one factor was s~mewhat different from each other, but when multiple regression line of four factors was used the estimation became more correct. Judging from these results, it is adequate to use the multiple regression equation of [4] and [4]' when we want to forecast the median date or mode date ofJapanese encephalitis time cure. 6) In the case of adding two factors concerned with mosquitoes to T6,7 (X¹), D. pos. swine (x²), latitude (x³), longitude (x4), multiple regression equations become as follows. y= -1.46x¹+0.14X²+0.068x5+89.03 σ= 6.9.. ·[5] z= -3. 29x¹+0 .13x²-0. 010x5+ 143.63 σ= 18.6··· [5]' y=-4.20x¹+0.35x²+0.29x6 + 53.70 σ= 4.2 .. ·[6] z=-2.56x¹-0.0lx²-0.02x6 +128.96 σ=11.4 [6]' y= 4.76x¹+0.41x²+0.13x5+0.22x6-72.78 σ= 4.5 [7] z = - 2. l0x¹ + 0. 05x²+ 0. 11 x5 - 0. 08x6+ 113.4 σ= 10. 7.. · [7]' where x5 is the time when the number of mosquitoes (C. T. collected by light trap reached the maximum and X6 is the time when hazardous mosq uitoes were dected. In the case of median date, 5 prefectures out of 6 prefectures by [5], 2 out of 6 by [6] and 2 out of 5 by [7], and in the case of mode date, 5 out of 6 by [5]', 4 out of 5 by [6]' and 4 out of 5 by [7]' could be accurately estimated in 1969.

The rate of transport of blood glutamic acid into the brain and the rate of metabolic conversion of the amino acid in the brain were derived by the use of the brain perfution method in vivo and in situ with [D.HC] ·Lglutamic acid. The net uptake of glutamic acid by the brain was observed. Most of the radioactivity released from the brain into the cerebral venous blood was found to consist of glutamine. Small but significant amounts of output as radioactive GSH and CO2 were also found. Glutamic acid transport and its rate of metabolism were lowered in the glucose. free condition. The size of the compartment of the small glutamic acid pool, which was related closely to the blood glutamic acid, and that of the large glutamic acid pool, which was related closely to the blood glucose, were calculated and compared with each other.

By assuming a three-compartment model, kinetic analysis of peripheral hyroxine distributions in various organs was represented by the alues calculated on the basis of the disappearance curve of 131I-T4 radioactivity in the serum, time　dependent curve of radioactivity over the liver　and urinary excretion of 131I-T4 in attempts to clarify the kinetic distribution　of the thyroxine and the time　dependent pool size of thyroxine in each　compartment such as serum pool, liver pool, and the other pool,　As a result it has been demonstrated that pool size3 of tyroxine, in the serum, liver and the other pool are enlarged in　hyperthyroidism, while　they are decreased in　hypothyroidism in respective pools.　We have recognized the reduction in the values of the liver pool size　of 131I-thyroxine and 131I-thyroxine excretion into the bile, while the increase　of 131I-thyroxine excretion into the urine in the cases of chronic hepatitis　and cirrhosis of the liver, but the thyroxine concentration in the serum to remain within the normal level in liver diseases. As a result of the reduction　in the liver pool size of 131I-thyroxine and in its uptake into the liver,　the other pool size enlarges to compensate the reduction and the function of the other pool is elevated.

For predicting median date or incidence rate in the prevalence of japanese encephalitis, the authors considered the 34 factors; namely, the climate, latitude, longitude, and date showing immunological positivity of hemoagglutination inhibiting reaction on 50% the number of swine, etc. To make the mean square residual the smallest which yields, in the case of calculating with the multiple regression equation, the most important and meritorious factors were selected from the factors mentioned above by the voluntary selection rule devised by us. Multiple regression equations were formulated for them. To predict the median date in the prevalence of japanese encephalitis in whole japan, we found that the three factors, i. e. the amount of rainfall in April, the average temperature in March and HI positive rate of swine till the end of july, were essential. And for the foreseeing of incidence rate in Okayama Prefecture, factors concerning mosquitoes were added; this resulted in the useful two factors, namely, common logarithm of the total number of Culex tritaeniorhynchus till july 20th and the rainfall in June.

We examined the method for determining microquantities of lipids, including cholesterol, cholesteryl esters and phospholipids. A standard colorimetric procedure of cholesteryl esters was modified to accommodate a quantitative thin-layer chromatography. This method involved the following steps. (1) Separation of lipids by a thin-layer chromatography: Lipids were applied to Silica gel G plates. Plates were developed with petroleum ether-diethyl etheracetic acid (82: 18: 2, vIvIv). (2) Elution of cholesterol and its esters from scraped silica gel: After scraping the silica gel with adhered cholesterol and its esters, they were eluted with chloroform-methanol (4: 1, v,tv). In the case of phspholipids, the silica gel was calcified. (3) Colorimetric determination of the lipids: Cholesterol and its esters eluted from the silica gel were determined by the method of ZAK with ROSENTHAL'S color reagent directly and after saponification, respectively. Phospholipids were calculated from the phosphorous content determined by the method of KATES. On the basis of examination of recovery and analyses of lipids extracted from tissue, it was concluded that this method permitted a reliable estimation of microquantities of cholesterol, its esters and phospholipids from small amounts of biological materials.

A new dynamic CT method for evaluating the portal blood flow is described. Thirty healthy volunteers were injected with non-ionic hypo-osmotic iodine contrast medium to estimate the portal blood flow. Time density curves (TD-curves) for the abdominal aorta and the main trunk of the portal vein were determined on the basis of data obtained by dynamic CT. From the TD-curves, portal blood flow coefficient and circulation time to flow into the portal vein (P-P time) were calculated. More detailed data of the TD-curves could be obtained by the new dynamic CT than by the previous methods. Subjects were simultaneously studied by an ultrasonic pulsed Doppler method which has been clinically accepted. There was a significant correlation between our dynamic CT method (portal blood flow coefficient) and the ultrasonic pulsed Doppler method concerning the measurement of portal blood flow. Therefore, it may be concluded that this CT method is reliable and clinically acceptable.