Meningococcal Disease Caused by Neisseria meningitidis Serogroup B Serotype 4 in São Paulo, Brazil, 1990 to 1996

A large epidemic of serogroup B meningococcal disease (MD), has been occurring in greater São Paulo, Brazil, since 1988.21 A Cuban-produced vaccine, based on outer-membrane-protein (OMP) from serogroup B: serotype 4: serosubtype P1.15 (B:4:P1.15) Neisseria meningitidis, was given to about 2.4 million children aged from 3 months to 6 years during 1989 and 1990. The administration of vaccine had little or no measurable effects on this outbreak. In order to detect clonal changes that could explain the continued increase in the incidence of disease after the vaccination, we serotyped isolates recovered between 1990 and 1996 from 834 patients with systemic disease. Strains B:4:P1.15, which was detected in the area as early as 1977, has been the most prevalent phenotype since 1988. These strains are still prevalent in the area and were responsible for about 68% of 834 serogroup B cases in the last 7 years. We analyzed 438 (52%) of these strains by restriction fragment length polymorphism (RFLPs) of rRNA genes (ribotyping). The most frequent pattern obtained was referred to as Rb1 (68%). We concluded that the same clone of B:4:P1.15-Rb1 strains was the most prevalent strain and responsible for the continued increase of incidence of serogroup B MD cases in greater São Paulo during the last 7 years in spite of the vaccination trial.

N-terminal amino acid sequences of the major outer membrane proteins from a Neisseria meningitidis group B strain isolated in Brazil

The four dominant outer membrane proteins (46, 38, 33 and 28 kDa) were detected by sodium dodecyl sulfate-polyacrylamide gel electrophoresis (SDS-PAGE) in a semi-purified preparation of vesicle membranes of a Neisseria meningitidis (N44/89, B:4:P1.15:P5.5,7) strain isolated in Brazil. The N-terminal amino acid sequence for the 46 kDa and 28 kDa proteins matched that reported by others for class 1 and 5 proteins respectively, whereas the sequence (25 amino acids) for the 38 kDa (class 3) protein was similar to class 1 meningococcal proteins. The sequence for the 33 kDa (class 4) was unique and not homologous to any known protein.

DI-HIDROCUCURBITACINA B: SEMI-SÍNTESE DE NOVOS DERIVADOS GLICOSILADOS

In the last ten years, the interest in natural and semi-synthetic cucurbitacin derivatives has increased, primarily due their cytotoxic and anti-tumoral activities. However, the isolation of glycosylated cucurbitacins has been difficult due the presence of β-glucosidase enzyme. With the aim of obtaining new glycosylated derivatives, the glycosylation of dihydrocucurbitacin B under Köenigs-Knorr and imidate reaction conditions was studied. Novel glycoside derivatives 16-(1,2-orthoacetate-3,4,6-tri-O-acetyl-α-D-glucopyranosyl)-dihydrocucurbitacin B (2), 2-O-β-D-2,3,4,6-tetra-O-acetyl-galactopyranosyl dihydrocucurbitacin B (3) and 2-O-β-D-galactopyranosyl dihydrocucurbitacin B (4) were synthesized for the first time in 17% (2 and 3) and 48% (4) yields.

Letalidade na epidemiologia da doença meningocócica: estudo na região de Campinas, SP, 1993 a 1998

OBJETIVO: Analisar a tendência da letalidade e da incidência da doença meningocócica no período de 1993 a 1998 na região de Campinas, SP, abrangendo cinco municípios de seu entorno (1,2 milhões de habitantes). MÉTODOS: Foi realizado estudo longitudinal retrospectivo de todos os casos notificados (375) da doença meningocócica pela vigilância epidemiológica regional. Por meio de análise de regressão logística foram identificados os fatores associados ao aumento da letalidade dessa doença. RESULTADOS: Os anos de 1996 e de 1997 apresentaram maiores coeficientes de letalidade (23,8%), coincidindo com picos de incidência do sorogrupo B, altos percentuais de meningococcemia e menor investigação etiológica. Observou-se padrão sazonal e predomínio da circulação da Neisseria meningitidis das cepas B:4:P1.15 e C:2b:P1.3. Os fatores relacionados com o aumento da letalidade pela análise de regressão logística foram: presença de meningococcemia, com ou sem meningite (odds ratio ajustado (ORaj) 13,88 e intervalo de confiança de 95% (IC) 4,68-42,13); idade acima de 30 anos (ORaj 6,42; IC 2,32-17,80); idade inferior a 1 ano (ORaj 2,95; IC 1,55-5,63); e sorogrupo B (ORaj 2,33; IC 1,14- 4,79). CONCLUSÕES: A septicemia, a idade e o sorogrupo mostraram-se variáveis preditoras de morte. Em alguns anos os coeficientes de letalidade apresentaram-se altos, indicando a necessidade de investigação da qualidade e da agilidade da assistência à saúde na prevenção dos óbitos. O percentual de identificação etiológica dos casos dificultou conclusões mais precisas sobre o comportamento epidemiológico das cepas.

Cyclophosphamide effect on coccidioidomycosis in the rat

Coccidioidomycosis is a systemic mycosis, endemic in arid areas of the American continent. The rat was employed as an experimental host, since it had been shown to reproduce human lesions and present a chronic course of disease with granulomas mainly restricted to lungs. Given the influence of immunosuppressive therapy on the clinical course of human coccidioidomycosis, we studied the effect of cyclophosphamide (CY) in the experimental rat model. Accordingly, animals were inoculated with 400 Coccidioides immitis arthroconidia of the Acosta strain, by intracardiacal route. As single CY doses failed to alter the course of disease, three schedules were used: A) 4 daily doses of 20 mg/kg each, prior to C. immitis inoculation; B) 4 similar daily doses after infection; and C); 6 doses of 20 mg/kg each, given from day +1 to +4, then on days +8 and +9, post infection (pi), taking day 0 as the time of fungal inoculation. The first two schedules inhibited antibody formation up to day 28 pi, without modifying cellular response to coccidioidin as measured by foodpad swelling. Initially, there was greater fungal spread than in controls receiving C. immitis alone, which proved self-limiting in the latter. In contrast, schedule C led to 559r mortality, with both humoral and cellular response abrogation, accompanied by extensive C. immitis dissemination. Histology disclosed significant alterations, such as the persistence of primary infection sporangia, corresponding to the acute stage of coccidioidomycosis in the absence of granuloma development. Therefore, the observed depression in cellular immunity seems responsible for the lack of inflammatory reaction capable of restricting sporangia proliferation in tissues which, in turn, enhances pathogen spread and mortality rate.

Subclinical Ventricular Dysfunction Detected by Speckle Tracking Two Years after Use of Anthracycline

Background: Heart failure is a severe complication associated with doxorubicin (DOX) use. Strain, assessed by two-dimensional speckle tracking (2D-STE), has been shown to be useful in identifying subclinical ventricular dysfunction. Objectives: a) To investigate the role of strain in the identification of subclinical ventricular dysfunction in patients who used DOX; b) to investigate determinants of strain response in these patients. Methods: Cross-sectional study with 81 participants: 40 patients who used DOX ±2 years before the study and 41 controls. All participants had left ventricular ejection fraction (LVEF) ≥55%. Total dose of DOX was 396mg (242mg/ms2). The systolic function of the LV was evaluated by LVEF (Simpson), as well as by longitudinal (εLL), circumferential (εCC), and radial (εRR) strains. Multivariate linear regression (MLR) analysis was performed using εLL (model 1) and εCC (model 2) as dependent variables. Results: Systolic and diastolic blood pressure values were higher in the control group (p < 0.05). εLL was lower in the DOX group (-12.4 ±2.6%) versus controls (-13.4 ± 1.7%; p = 0.044). The same occurred with εCC: -12.1 ± 2.7% (DOX) versus -16.7 ± 3.6% (controls; p < 0.001). The S’ wave was shorter in the DOX group (p = 0.035). On MLR, DOX was an independent predictor of reduced εCC (B = -4.429, p < 0.001). DOX (B = -1.289, p = 0.012) and age (B = -0.057, p = 0.029) were independent markers of reduced εLL. Conclusion: a) εLL, εCC and the S’ wave are reduced in patients who used DOX ±2 years prior to the study despite normal LVEF, suggesting the presence of subclinical ventricular dysfunction; b) DOX was an independent predictor of reduced εCC; c) prior use of DOX and age were independent markers of reduced εLL.

A determinação dos números de indivíduos mínimos necessários na experimentação genética

The main object of the present paper consists in giving formulas and methods which enable us to determine the minimum number of repetitions or of individuals necessary to garantee some extent the success of an experiment. The theoretical basis of all processes consists essentially in the following. Knowing the frequency of the desired p and of the non desired ovents q we may calculate the frequency of all possi- ble combinations, to be expected in n repetitions, by expanding the binomium (p-+q)n. Determining which of these combinations we want to avoid we calculate their total frequency, selecting the value of the exponent n of the binomium in such a way that this total frequency is equal or smaller than the accepted limit of precision n/pª{ 1/n1 (q/p)n + 1/(n-1)| (q/p)n-1 + 1/ 2!(n-2)| (q/p)n-2 + 1/3(n-3) (q/p)n-3... < Plim - -(1b) There does not exist an absolute limit of precision since its value depends not only upon psychological factors in our judgement, but is at the same sime a function of the number of repetitions For this reasen y have proposed (1,56) two relative values, one equal to 1-5n as the lowest value of probability and the other equal to 1-10n as the highest value of improbability, leaving between them what may be called the "region of doubt However these formulas cannot be applied in our case since this number n is just the unknown quantity. Thus we have to use, instead of the more exact values of these two formulas, the conventional limits of P.lim equal to 0,05 (Precision 5%), equal to 0,01 (Precision 1%, and to 0,001 (Precision P, 1%). The binominal formula as explained above (cf. formula 1, pg. 85), however is of rather limited applicability owing to the excessive calculus necessary, and we have thus to procure approximations as substitutes. We may use, without loss of precision, the following approximations: a) The normal or Gaussean distribution when the expected frequency p has any value between 0,1 and 0,9, and when n is at least superior to ten. b) The Poisson distribution when the expected frequecy p is smaller than 0,1. Tables V to VII show for some special cases that these approximations are very satisfactory. The praticai solution of the following problems, stated in the introduction can now be given: A) What is the minimum number of repititions necessary in order to avoid that any one of a treatments, varieties etc. may be accidentally always the best, on the best and second best, or the first, second, and third best or finally one of the n beat treatments, varieties etc. Using the first term of the binomium, we have the following equation for n: n = log Riim / log (m:) = log Riim / log.m - log a --------------(5) B) What is the minimun number of individuals necessary in 01der that a ceratin type, expected with the frequency p, may appaer at least in one, two, three or a=m+1 individuals. 1) For p between 0,1 and 0,9 and using the Gaussean approximation we have: on - ó. p (1-p) n - a -1.m b= δ. 1-p /p e c = m/p } -------------------(7) n = b + b² + 4 c/ 2 n´ = 1/p n cor = n + n' ---------- (8) We have to use the correction n' when p has a value between 0,25 and 0,75. The greek letters delta represents in the present esse the unilateral limits of the Gaussean distribution for the three conventional limits of precision : 1,64; 2,33; and 3,09 respectively. h we are only interested in having at least one individual, and m becomes equal to zero, the formula reduces to : c= m/p o para a = 1 a = { b + b²}² = b² = δ2 1- p /p }-----------------(9) n = 1/p n (cor) = n + n´ 2) If p is smaller than 0,1 we may use table 1 in order to find the mean m of a Poisson distribution and determine. n = m: p C) Which is the minimun number of individuals necessary for distinguishing two frequencies p1 and p2? 1) When pl and p2 are values between 0,1 and 0,9 we have: n = { δ p1 ( 1-pi) + p2) / p2 (1 - p2) n= 1/p1-p2 }------------ (13) n (cor) We have again to use the unilateral limits of the Gaussean distribution. The correction n' should be used if at least one of the valors pl or p2 has a value between 0,25 and 0,75. A more complicated formula may be used in cases where whe want to increase the precision : n (p1 - p2) δ { p1 (1- p2 ) / n= m δ = δ p1 ( 1 - p1) + p2 ( 1 - p2) c= m / p1 - p2 n = { b2 + 4 4 c }2 }--------- (14) n = 1/ p1 - p2 2) When both pl and p2 are smaller than 0,1 we determine the quocient (pl-r-p2) and procure the corresponding number m2 of a Poisson distribution in table 2. The value n is found by the equation : n = mg /p2 ------------- (15) D) What is the minimun number necessary for distinguishing three or more frequencies, p2 p1 p3. If the frequecies pl p2 p3 are values between 0,1 e 0,9 we have to solve the individual equations and sue the higest value of n thus determined : n 1.2 = {δ p1 (1 - p1) / p1 - p2 }² = Fiim n 1.2 = { δ p1 ( 1 - p1) + p1 ( 1 - p1) }² } -- (16) Delta represents now the bilateral limits of the : Gaussean distrioution : 1,96-2,58-3,29. 2) No table was prepared for the relatively rare cases of a comparison of threes or more frequencies below 0,1 and in such cases extremely high numbers would be required. E) A process is given which serves to solve two problemr of informatory nature : a) if a special type appears in n individuals with a frequency p(obs), what may be the corresponding ideal value of p(esp), or; b) if we study samples of n in diviuals and expect a certain type with a frequency p(esp) what may be the extreme limits of p(obs) in individual farmlies ? I.) If we are dealing with values between 0,1 and 0,9 we may use table 3. To solve the first question we select the respective horizontal line for p(obs) and determine which column corresponds to our value of n and find the respective value of p(esp) by interpolating between columns. In order to solve the second problem we start with the respective column for p(esp) and find the horizontal line for the given value of n either diretly or by approximation and by interpolation. 2) For frequencies smaller than 0,1 we have to use table 4 and transform the fractions p(esp) and p(obs) in numbers of Poisson series by multiplication with n. Tn order to solve the first broblem, we verify in which line the lower Poisson limit is equal to m(obs) and transform the corresponding value of m into frequecy p(esp) by dividing through n. The observed frequency may thus be a chance deviate of any value between 0,0... and the values given by dividing the value of m in the table by n. In the second case we transform first the expectation p(esp) into a value of m and procure in the horizontal line, corresponding to m(esp) the extreme values om m which than must be transformed, by dividing through n into values of p(obs). F) Partial and progressive tests may be recomended in all cases where there is lack of material or where the loss of time is less importent than the cost of large scale experiments since in many cases the minimun number necessary to garantee the results within the limits of precision is rather large. One should not forget that the minimun number really represents at the same time a maximun number, necessary only if one takes into consideration essentially the disfavorable variations, but smaller numbers may frequently already satisfactory results. For instance, by definition, we know that a frequecy of p means that we expect one individual in every total o(f1-p). If there were no chance variations, this number (1- p) will be suficient. and if there were favorable variations a smaller number still may yield one individual of the desired type. r.nus trusting to luck, one may start the experiment with numbers, smaller than the minimun calculated according to the formulas given above, and increase the total untill the desired result is obtained and this may well b ebefore the "minimum number" is reached. Some concrete examples of this partial or progressive procedure are given from our genetical experiments with maize.

Absorção de nutrientes pela amoreira Morus alba L

Com o intuito de se conhecer os teores porcentuais dos macronutrientes e as concentrações em ppm dos micronutrientes; assim como, a quantidade total dos nutrientes extraída pela cultura da amoreira (Morus alba L.), colheu-se folhas e ramos de um certo número de pés em épocas diferentes. O material após analisado revelou que o N apresenta-se em maior concentração, sendo seguido pelo K, Ca, Mg, P e S. Dentre os micronutrientes o Fe apresentou maior concentração, seguido pelo Mh, Zn, B e Cu. Os autores determinaram que uma planta de amoreira extraiu as seguintes quantidades dos nutrientes: N-22g; P-l,6g; K-18,5g; Ca-13,3g; Mg-3,5g; S-1,2g; B-4,7ug; Cu-6,5ug; Fe-109ug; Mn-70,6ug; Zn-30ug.

Nutrição mineral do cajueiro (Anacardium occidentale L.): III - absorção de nutrientes - nota prévia

Na presente nota prévia os autores apresentam os primeiros dados acerca da extração e exportação de nutrientes através do cajueiro a partir de 1 a 14 anos de idade. As plantas foram colhidas de uma plantação localizada no Município de Terezinha, BA, situadas em um latossolo de baixa fertilidade, exceto em K. As plantas foram pesadas e analisadas para N, P, K, Ca, Mg, S, B, Cu, Fe, Mn e Zn. Constataram os autores que o cajueiro cresce continuamente até aos 14 anos. Uma árvore aos 10 anos de idade contém: N- 1,5 kg; P- 0,2 kg; K- 1,1 kg; Ca-0,2 kg;Mg-0,3 kg; S- 0,1 kg; B- 4,0 g;Cu-1,4 g;Fe- 2,0 g;Mn- 7,8 g;Zn- 2,6 g. Aquilataram os autores que a exportação de nutrientes através de 1 kg de frutos é a seguinte: N- 13,9 g; P- 1,3 g; K- 6,2 g; Ca- 0,3 g; Mg- 1,3 g; S- 0,5 g; B-18,5 mg; Cu-16,2 mg; Fe- 36,9 mg; Mn-13,2 mg. Finalmente observaram que a concentração de N, Mg, S, Cu, Fe e Zn não varia nas folhas em função da idade da planta; sendo que a concentração em P, K, Ca, B e Mn varia com a idade da planta.

Typing and susceptibility to penicillin of Neisseria meningitidis isolated from patients in Cuba (1993-1999)

The susceptibility to penicillin of 111 Neisseria meningitidis strains was assessed by the agar-dilution procedure and serosubtypes were determined by a whole-cell enzyme-linked immunoassay using monoclonal antibodies reagents. Thirty-five isolates showed reduced sensitivity to penicillin (MIC > or = 0.1 mg/l and <= 1 mg/l) and no resistant strains were detected. The most common phenotype was B:4:P1.15 (77.5%) and a rising trend of non-typeable and non-subtypeable strains was detected. The increase in levels of minimal inhibitory concentrations of meningococci to penicillin gives cause for concern and the increase in non-typeable and non-subtypeable isolation demand the use of molecular biology techniques for their typing.

Substâncias antifúngicas de Xylaria sp., um fungo endofítico isolado de Palicourea marcgravii (Rubiaceae)

Five compounds, 2-hexyl-3-methyl-butanodioic acid (1), cytochalasin D (2), 7-dechlorogriseofulvin (3), cytochalasin B (4) and griseofulvin (5), have been isolated from the endophytic fungus Xylaria sp., and their structures were elucidated on the basis of spectroscopic data. In the bioautography assay against Cladosporium cladosporioides and Cladosporium sphaerospermum, compounds 1 and 2 were found to be active while compounds 3, 4 and 5 did not show antifungal activity.

Conteúdo e exportação de micronutrientes em acácia-negra (Acacia Mearnsii De Wild.) procedência batemans bay (Austrália)

O objetivo do presente trabalho foi estimar o conteúdo e a exportação de micronutrientes (Mn, B, Cu, Zn e Fe) e o Na nos diferentes componentes de árvores de um povoamento de acácia-negra (Acacia mearnsii De Wild.), procedência australiana Batemans Bay, com 2,4 anos de idade, em Butiá-RS (Brasil). A biomassa total estimada foi de 36.155 kg/ha, apresentando distribuição de 46,0, 20,0, 19,5, 12,0 e 3,0%, na madeira do lenho, nas folhas, nos galhos vivos, na casca e nos galhos mortos, respectivamente. A proporção de micronutrientes acumulados na biomassa dos componentes da árvore foram 43,76% nas folhas, 26,94% na madeira do tronco, 19,56% nos galhos vivos, 7,21% na casca e 2,54% nos galhos mortos. A quantidade estimada de micronutrientes contidos na biomassa acima do solo foi 10,4 kg/ha, acumulados da seguinte forma: Na (58,84%), Fe (21,79%), Zn (9,16%), B (4,09%), Mn (4,59%) e Cu (1,54%). A casca e a madeira do lenho acumulou Na (21,47%), Fe (6,71%), Mn (2,11%), Zn (1,66%), B (1,58%) e Cu (0,63%). A copa (folhas e galhos vivos e mortos) acumularam Na (37,36%), Fe (15,07%), Zn (7,49%), B (2,53%), Mn (2,48%) e Cu (0,91%). A exploração intensiva de áreas com a procedência Batemans Bay gera suspeitas de possíveis ocorrências de deficiências nutricionais de Na nas rotações futuras, tornando necessário o emprego de fertilizantes para manter a produtividade do sítio.

Avaliação da Atividade Proliferativa no Epitélio Mamário Adjacente a Fibroadenoma em Mulheres Tratadas com Tamoxifeno

Objetivo: estudar a atividade proliferativa do epitélio mamário normal adjacente a fibroadenoma em mulheres na fase lútea do ciclo menstrual, tratadas com tamoxifeno. Pacientes e Métodos: estudou-se por técnica imuno-histoquímica, com o uso do anticorpo monoclonal MIB-1, a atividade proliferativa no epitélio mamário adjacente a fibroadenoma. O estudo foi randomizado e duplo-cego. As 44 mulheres com fibroadenoma foram divididas em 3 grupos: A (n = 16; placebo), B (n = 15; tamoxifeno, 10 mg) e C (n = 13; tamoxifeno, 20 mg). O tamoxifeno foi utilizado por 22 dias, a partir do 2º dia do ciclo menstrual, e a biópsia realizada no 23º dia. Resultados: a porcentagem média de núcleos corados por 1000 células no grupo A foi 9,2, no grupo B, 4,5, e no grupo C, 3,2. O teste de Fisher revelou que o tamoxifeno reduziu de forma significante a imunoexpressão do MIB-1 nas doses de 10 e 20 mg em comparação com o grupo placebo (p<0,0001) e não houve variação significante da atividade proliferativa nas doses de 10 e 20 mg de tamoxifeno (p = 0,21). Conclusão: conclui-se que o tamoxifeno reduziu de forma significante a atividade proliferativa do epitélio mamário, nas doses de 10 e 20 mg/dia.

Genetic relationships among serogroup B: serotype 4 Neisseria meningitidis strains

We compared the results obtained by serotyping of PorB epitopes using an expanded panel of monoclonal antibodies (mAb) including mAb 7 and mAb 10, with results obtained by RFLP of rRNA genes (ribotyping). The purpose of this study was to assess the correlation between phenotypic- and genotypic- methods for typing N. meningitidis. The ribotypes obtained using ClaI or EcoRV endonucleases grouped the strains in seven and two different patterns, respectively. This additional characterization of PorB epitopes improved the correlation between these two methods of typing N. meningitidis.

DESENVOLVIMENTO DE ÁRVORES NATIVAS EM ENSAIOS DE ESPÉCIES. 4. CASTANHA-DO-BRASIL (Bertholletia excelsa Η. B. K.), DEZ ANOS APÓS O PLANTIO

Três parcelas experimentais de Bertholletia excelsa (Castanha-do- Brasil) foram implantadas na Estação Experimental de Silvicultura Tropical do INPA/Manaus, em 1980, com o objetivo de obter dados sobre o crescimento da espécie com fins de produção de madeira e frutos. O sistema de plantio adotado foi em plena abertura, sobre Latossolo vermelho-amarelo, no espaçamento de 3,0 x 3,0 m. Foram observados, aos 10 anos, os seguintes resultados, diâmetro médio (DAP) de 13,9 cm e a altura total média de 15,41 m; os valores máximos de diâmetros e alturas encontrados foram de 21,7 cm e 23,0 m. respectivamente; a área basal média por hectare foi de 11,7098 nr. correspondendo a um volume médio de 117391 m3/ha; a espécie apresentou ótima desrama natural, boa adaptação ao Latossolo vermelho - amarelo, 69,44% de sobrevivência média, boa forma de fuste, não tendo sido verificadas doenças ou pragas.