Obstrucao Coronaria apos Implante por Cateter de Protese Valvar Aortica

Fundamentos: O implante por cateter de bioprótese valvar aórtica (TAVI) consolidou-se como alternativa para o tratamento de pacientes com estenose aórtica importante de alto risco cirúrgico. Contudo, há poucos dados na literatura com respeito à obstrução coronária que, apesar de rara, trata-se de grave complicação do TAVI. Objetivo: Avaliar, no contexto brasileiro, a presença dessa importante complicação. Métodos: Foram avaliados todos os casos de obstrução coronária incluídos no Registro Brasileiro de TAVI. Foram coletados dados clínicos, do procedimento, do manejo e de evolução intra-hospitalar. Resultados: Entre 418 pacientes consecutivos do registro, ocorreram três casos de obstrução coronária (incidência de 0,72%). Em sua totalidade, os pacientes eram do sexo feminino, sem cirurgia de revascularização miocárdica (CRM) prévia, com idade média de 85 ± 3 anos, EuroSCORE logístico de 15 ± 6% e STS de 9 ± 4%. Todos os casos foram realizados com a válvula balão-expansível Sapien XT. Em um dos pacientes, com dados de tomografia computadorizada pré-procedimento, verificaram-se origem das artérias coronárias baixa e seio de Valsalva estreito. Todos os pacientes apresentaram-se clinicamente com hipotensão importante e mantida, imediatamente após o implante da válvula, e, apesar de angioplastia com implante de stent, todos os pacientes foram a óbito, sendo dois periprocedimento e um durante hospitalização. Conclusão: A obstrução coronária como complicação do TAVI, apesar de rara, é potencialmente fatal, podendo ocorrer mais frequentemente em mulheres e com as próteses expansíveis por balão. Fatores anatômicos podem estar relacionados com sua ocorrência, ressaltando-se a importância de boa avaliação pré-procedimento no sentido de evitar essa grave complicação.

Escore Prognóstico para Síndrome Coronariana Aguda em Hospital Terciário Privado

Fundamento: Os modelos prognósticos disponíveis para Síndrome Coronariana Aguda (SCA) podem ter limitações de performance, por terem sido elaborados há vários anos, ou problemas de aplicabilidade. Objetivos: Elaborar escores para predição de eventos desfavoráveis em 30 dias e 6 meses, em pacientes com SCA, com ou sem Supradesnivelamento de ST (SST), atendida em hospital privado terciário. Métodos: Coorte prospectiva de pacientes consecutivos com SCA admitidos entre agosto/2009 a junho/2012. O desfecho primário composto foi a ocorrência de óbito, infarto ou reinfarto, Acidente Vascular Cerebral (AVC), parada cardiorrespiratória e sangramento maior. As variáveis preditoras foram selecionadas de dados clínicos, laboratoriais, eletrocardiográficos e da terapêutica. O modelo final foi obtido por meio de regressão logística e submetido a validação interna, utilizando-se bootstraping. Resultados: Incluímos 760 pacientes, 132 com SCA com SST e 628 sem SST. A idade média foi 63,2 ± 11,7 anos, sendo 583 homens (76,7%). O modelo final para eventos em 30 dias contém cinco preditores: idade ≥ 70 anos, antecedente de neoplasia, Fração de Ejeção do Ventrículo Esquerdo (FEVE) < 40%, troponinaI > 12,4 ng/mL e trombólise. Na validação interna, o modelo mostrou ter boa performance com área sob a curva de 0,71.Os preditores do modelo para 6 meses são: antecedente de neoplasia, FEVE < 40%, trombólise, troponina I > 14,3 ng/mL, creatinina > 1,2 mg/dL, antecedente de doença pulmonar obstrutiva crônica e hemoglobina < 13,5 g/dL. Na validação interna, o modelo apresentou boa performance com área sob a curva de 0,69. Conclusões: Desenvolvemos escores de fácil utilização e boa performance para predição de eventos adversos em 30 dias e 6 meses em pacientes com SCA.

Parâmetros Ecocardiográficos e Sobrevida na Cardiopatia Chagásica com Disfunção Sistólica Importante

Fundamento: O ecocardiograma fornece dados importantes na avaliação cardiológica de pacientes em insuficiência cardíaca. A identificação de parâmetros ecocardiográficos na cardiopatia chagásica grave auxiliaria na implementação terapêutica e na avaliação prognóstica. Objetivo: Correlacionar parâmetros ecocardiográficos com desfecho mortalidade cardiovascular em pacientes com fração de ejeção < 35%. Métodos: Estudo de análise retrospectiva de parâmetros ecocardiográficos coletados prospectivamente e pré-especificados em 60 pacientes incluídos no Estudo Multicêntrico Randomizado de Terapia Celular em Cardiopatias - braço cardiopatia chagásica. Os parâmetros foram: diâmetros e volumes diastólico e sistólico do ventrículo esquerdo, fração de ejeção, diâmetro do átrio esquerdo, volume do átrio esquerdo, volume indexado do átrio esquerdo, pressão sistólica da artéria pulmonar, integral da velocidade do fluxo aórtico, índice de performance miocárdica, taxa de aumento da pressão do ventrículo esquerdo, tempo de relaxamento isovolumétrico, velocidade das ondas E, A, Em, Am e Sm, tempo de desaceleração da onda E, relação E/A , E/Em e insuficiência mitral. Resultados: No seguimento médio de 24,18 meses, 27 pacientes faleceram. a fração de ejeção média era de 26,6 ± 5,34%. Na análise multivariada, foram incluídos os parâmetros de fração de ejeção (HR = 1,114; p = 0,3704), volume indexado do átrio esquerdo (HR = 1,033; p < 0,0001) e relação E/Em (HR = 0,95; p = 0,1261). O volume indexado do átrio esquerdo foi um fator de predição independente em relação ao desfecho e observou-se que um valor > 70,71 mL/m2 foi associado ao aumento significativo na mortalidade (log rank p < 0,0001). Conclusão: O volume indexado do átrio esquerdo mostrou-se como único fator de predição independente de mortalidade nesta população de pacientes chagásicos e com disfunção sistólica importante.

Experiência Inicial de Dois Centros Nacionais no Implante de Prótese Aórtica Transcateter

Fundamento: O implante de prótese aórtica transcateter é uma alternativa efetiva para o tratamento cirúrgico para a correção de estenose aórtica grave em pacientes inoperáveis ou de alto risco cirúrgico. Objetivos: Apresentar os resultados clínicos e ecocardiográficos imediatos e no médio prazo da experiência inicial do implante de prótese aórtica transcateter. Métodos: Entre junho de 2009 e fevereiro de 2013, 112 pacientes foram submetidos a implante de prótese aórtica transcateter. Resultados: A idade média foi 82,5 ± 6,5 anos e o Euro SCORE logístico foi 23,6 ± 13,5. O sucesso do procedimento foi de 84%. Após o implante, houve queda do gradiente sistólico médio (pré = 54,7 ± 15,3 mmHg vs. pós = 11,7 ± 4,0 mmHg; p < 0,01). Acidente vascular cerebral ocorreu em 3,6% dos pacientes, complicações vasculares em 19%, e foi necessário o implante de marca-passo definitivo em 13% dos pacientes nos primeiros 30 dias pós-implante. A mortalidade aos 30 dias e no seguimento médio de 16 ± 11 meses foi, respectivamente, de 14 e de 8,9%. A presença de doença pulmonar obstrutiva crônica foi o único preditor de mortalidade em 30 dias e no seguimento. A área valvar aórtica e o gradiente sistólico médio não apresentaram variações significativas durante o seguimento. Conclusões: O implante de prótese aórtica transcateter é um procedimento eficaz e seguro para o tratamento da estenose aórtica em pacientes de alto risco cirúrgico ou inoperáveis. A presença de doença pulmonar obstrutiva crônica foi o único preditor independente de mortalidade identificado, tanto no primeiro mês pós-intervenção quanto no seguimento mais tardio.

Survival and Predictive Factors of Lethality in Hemodyalisis: D/I Polymorphism of The Angiotensin I-Converting Enzyme and of the Angiotensinogen M235T Genes

Background: End-stage kidney disease patients continue to have markedly increased cardiovascular disease morbidity and mortality. Analysis of genetic factors connected with the renin-angiotensin system that influences the survival of the patients with end-stage kidney disease supports the ongoing search for improved outcomes. Objective: To assess survival and its association with the polymorphism of renin-angiotensin system genes: angiotensin I-converting enzyme insertion/deletion and angiotensinogen M235T in patients undergoing hemodialysis. Methods: Our study was designed to examine the role of renin-angiotensin system genes. It was an observational study. We analyzed 473 chronic hemodialysis patients in four dialysis units in the state of Rio de Janeiro. Survival rates were calculated by the Kaplan-Meier method and the differences between the curves were evaluated by Tarone-Ware, Peto-Prentice, and log rank tests. We also used logistic regression analysis and the multinomial model. A p value ≤ 0.05 was considered to be statistically significant. The local medical ethics committee gave their approval to this study. Results: The mean age of patients was 45.8 years old. The overall survival rate was 48% at 11 years. The major causes of death were cardiovascular diseases (34%) and infections (15%). Logistic regression analysis found statistical significance for the following variables: age (p = 0.000038), TT angiotensinogen (p = 0.08261), and family income greater than five times the minimum wage (p = 0.03089), the latter being a protective factor. Conclusions: The survival of hemodialysis patients is likely to be influenced by the TT of the angiotensinogen M235T gene.

Assessment of Autonomic Function by Phase Rectification of RRInterval Histogram Analysis in Chagas Disease

Background:In chronic Chagas disease (ChD), impairment of cardiac autonomic function bears prognostic implications. Phase‑rectification of RR-interval series isolates the sympathetic, acceleration phase (AC) and parasympathetic, deceleration phase (DC) influences on cardiac autonomic modulation.Objective:This study investigated heart rate variability (HRV) as a function of RR-interval to assess autonomic function in healthy and ChD subjects.Methods:Control (n = 20) and ChD (n = 20) groups were studied. All underwent 60-min head-up tilt table test under ECG recording. Histogram of RR-interval series was calculated, with 100 ms class, ranging from 600–1100 ms. In each class, mean RR-intervals (MNN) and root-mean-squared difference (RMSNN) of consecutive normal RR-intervals that suited a particular class were calculated. Average of all RMSNN values in each class was analyzed as function of MNN, in the whole series (RMSNNT), and in AC (RMSNNAC) and DC (RMSNNDC) phases. Slopes of linear regression lines were compared between groups using Student t-test. Correlation coefficients were tested before comparisons. RMSNN was log-transformed. (α < 0.05).Results:Correlation coefficient was significant in all regressions (p < 0.05). In the control group, RMSNNT, RMSNNAC, and RMSNNDCsignificantly increased linearly with MNN (p < 0.05). In ChD, only RMSNNAC showed significant increase as a function of MNN, whereas RMSNNT and RMSNNDC did not.Conclusion:HRV increases in proportion with the RR-interval in healthy subjects. This behavior is lost in ChD, particularly in the DC phase, indicating cardiac vagal incompetence.

One-year Mortality after an Acute Coronary Event and its Clinical Predictors: The ERICO Study

Background:Information about post-acute coronary syndrome (ACS) survival have been mostly short-term findings or based on specialized, cardiology referral centers.Objectives:To describe one-year case-fatality rates in the Strategy of Registry of Acute Coronary Syndrome (ERICO) cohort, and to study baseline characteristics as predictors.Methods:We analyzed data from 964 ERICO participants enrolled from February 2009 to December 2012. We assessed vital status by telephone contact and official death certificate searches. The cause of death was determined according to the official death certificates. We used log-rank tests to compare the probabilities of survival across subgroups. We built crude and adjusted (for age, sex and ACS subtype) Cox regression models to study if the ACS subtype or baseline characteristics were independent predictors of all-cause or cardiovascular mortality.Results:We identified 110 deaths in the cohort (case-fatality rate, 12.0%). Age [Hazard ratio (HR) = 2.04 per 10 year increase; 95% confidence interval (95%CI) = 1.75–2.38], non-ST elevation myocardial infarction (HR = 3.82 ; 95%CI = 2.21–6.60) or ST elevation myocardial infarction (HR = 2.59; 95%CI = 1.38–4.89) diagnoses, and diabetes (HR = 1.78; 95%CI = 1.20‑2.63) were significant risk factors for all-cause mortality in the adjusted models. We found similar results for cardiovascular mortality. A previous coronary artery disease diagnosis was also an independent predictor of all-cause mortality (HR = 1.61; 95%CI = 1.04–2.50), but not for cardiovascular mortality.Conclusion:We found an overall one-year mortality rate of 12.0% in a sample of post-ACS patients in a community, non-specialized hospital in São Paulo, Brazil. Age, ACS subtype, and diabetes were independent predictors of poor one‑year survival for overall and cardiovascular-related causes.

Aortic Counterpulsation Therapy in Patients with Advanced Heart Failure: Analysis of the TBRIDGE Registry

Abstract Background: The use of aortic counterpulsation therapy in advanced heart failure is controversial. Objectives: To evaluate the hemodynamic and metabolic effects of intra-aortic balloon pump (IABP) and its impact on 30-day mortality in patients with heart failure. Methods: Historical prospective, unicentric study to evaluate all patients treated with IABP betwen August/2008 and July/2013, included in an institutional registry named TBRIDGE (The Brazilian Registry of Intra-aortic balloon pump in Decompensated heart failure - Global Evaluation). We analyzed changes in oxygen central venous saturation (ScvO2), arterial lactate, and use of vasoactive drugs at 48 hours after IABP insertion. The 30-day mortality was estimated by the Kaplan-Meier method and diferences in subgroups were evaluated by the Log-rank test. Results: A total of 223 patients (mean age 49 ± 14 years) were included. Mean left ventricle ejection fraction was 24 ± 10%, and 30% of patients had Chagas disease. Compared with pre-IABP insertion, we observed an increase in ScvO2 (50.5% vs. 65.5%, p < 0.001) and use of nitroprusside (33.6% vs. 47.5%, p < 0.001), and a decrease in lactate levels (31.4 vs. 16.7 mg/dL, p < 0.001) and use of vasopressors (36.3% vs. 25.6%, p = 0.003) after IABP insertion. Thirty-day survival was 69%, with lower mortality in Chagas disease patients compared without the disease (p = 0.008). Conclusion: After 48 hours of use, IABP promoted changes in the use of vasoactive drugs, improved tissue perfusion. Chagas etiology was associated with lower 30-day mortality. Aortic counterpulsation therapy is an effective method of circulatory support for patients waiting for heart transplantation.

Serial High-Sensitivity Troponin T in Post-Primary Angioplasty Exercise Test

Abstract Background: The kinetics of high-sensitivity troponin T (hscTnT) release should be studied in different situations, including functional tests with transient ischemic abnormalities. Objective: To evaluate the release of hscTnT by serial measurements after exercise testing (ET), and to correlate hscTnT elevations with abnormalities suggestive of ischemia. Methods: Patients with acute ST-segment elevation myocardial infarction (STEMI) undergoing primary angioplasty were referred for ET 3 months after infarction. Blood samples were collected to measure basal hscTnT immediately before (TnT0h), 2 (TnT2h), 5 (TnT5h), and 8 hours (TnT8h) after ET. The outcomes were peak hscTnT, TnT5h/TnT0h ratio, and the area under the blood concentration-time curve (AUC) for hscTnT levels. Log-transformation was performed on hscTnT values, and comparisons were assessed with the geometric mean ratio, along with their 95% confidence intervals. Statistical significance was assessed by analysis of covariance with no adjustment, and then, adjusted for TnT0h, age and sex, followed by additional variables (metabolic equivalents, maximum heart rate achieved, anterior wall STEMI, and creatinine clearance). Results: This study included 95 patients. The highest geometric means were observed at 5 hours (TnT5h). After adjustments, peak hscTnT, TnT5h/TnT0h and AUC were 59% (p = 0.002), 59% (p = 0.003) and 45% (p = 0.003) higher, respectively, in patients with an abnormal ET as compared to those with normal tests. Conclusion: Higher elevations of hscTnT may occur after an abnormal ET as compared to a normal ET in patients with STEMI.

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.

A lei de Mitscherlich aplicada a experimentos de adubação com vinhaça

The author studies, with the aid of Mitscherlich's law, two experiments of sugar cane fertilization with vinasse. The first one, carried out in Piracicaba, State of S. Paulo, by ARRUDA, gave the following yields. No vinasse 47.0 tons/ha. 76.0 tons/ha. 250 c.m./ha. of vinasse 75.0 do. 112.0 do. 500 do. 90.0 do. 112.0 do. 1000 do. 98.0 do. 107.0 do. Data without NPK were appropriate for the fitting of the law, the equation of which was found to be: y = 100.8 [1 - 10 -0.00132 (x + 206) ], where y is measured in metric tons/hectare, and x in cubic meters/hectare. The optimum amount of vinasse to be used is given by the formula x* = 117.2 + 1 log w u , ______ ____ 0.00132 250 t being u the response to the standard dressing of 250 cubic meters/hectare of vinasse, w the price per ton of sugar cane, and t the price per cubic meter for the transportation of vinasse. In Pernambuco, a 3(4) NPK vinasse experiment gave the following mean yields: No vinasse 41.0 tons/hectare 250 cm./ha. of vinasse 108.3 do. 500 do. 134.3 do. The equation obtained was now y = 150.7 [1 - 10 -000165 (x + 84)], being the most profitable level of vinasse x* = 115.2 + 1 log w u , _______ ____ 0.00165 250 t One should notice the close agreement of the coefficients c (0.00132 in S. Paulo and 0.00165 in Pernambuco). Given the prices of Cr$ 20.00 per cubic meter for the transportation of vinasse (in trucks) and Cr$ 250.00 per ton of sugar cane (uncut, in the fields) the most profitable dressings are: 236 c.m./ha. of vinasse in S. Paulo, and 434 c.m./ha. in Pernambuco.

Sôbre uma fórmula para o cálculo da dose mais econômica de adubo

The authors discuss a formula for the determination of the most profitable level of fertilization (x*). This formula, presented by CAREY and ROBINSON (1953), can be written as: x*= (1/c) log cx u L10 + (1/c) log wu _______ ___ 1-10 x u t being c the growth factor in Mitscherlich's equation, x u a standard dressing of the nutrient, L 10 the Naeperian logarithm of 10, u the response to the standard dressing, w the unit price of the crop product, and i the unit price of the nutrient. This formula is a modification of one of the formulas of PIMENTEL GOMES (1953). One of its advantages is that is does not depend on A, the theoretical maximum harvest, which is not directly given by experimental data. But another advantage, proved in this. paper, is that the first term on the right hand side K= 1(/c) log cx u L 10 ____________ 1 - 10-cx u is practically independent of c, and approximately equivalent to (1/2) x u. So, we have approximately x* = (1/2) x u + (1/c) log wu . ____ x u t With experimental data we compute z = wu ____ x u t then using tables 1, 2 and 3, we may obtain Y - (1/c) log z and finally x* = (1/2) x u + Y. This is an easy way to determine the most profitable level of fertilization when experimental data on the response u to a dressing x u are available. Tables for the calculation of Y are included, for nitrogen, phosphorus, potash, and manure.

"O pH de soluções de ácido acético, cítrico, oxálico e tartárico"

O presente trabalho descreve os dados obtidos sôbre a determinação do pH em soluções, desde 0,005 até 0,50 molar de ácido acético, ácido cítrico, ácido oxálico e ácido tartárico. Os dados obtidos experimentalmente, quando expressos em função de pC, isto é, em função de log log 1/C apresentaram uma relação linear. Por outro lado, calculando-se o pH das diversas soluções dos ácidos estudados, através de duas equações, uma do primeiro grau e outra do segundo grau, observou-se que os resultados calculados pela segunda equação apresentaram valores muito próximos aos determinados experimentalmente, conquanto no cálculo tenha sido usada apenas, a primeira constante termodinâmica de ionização, para os ácido cítrico, oxálico e tartárico. Uma vez que o valor do pH determinado e o do pH calculado constituem uma função linear do pC, foram estabelecidas duas equações de regressão para cada ácido estudado. Na primeira equação de regressão o pH determinado figura como variável dependente e na segunda, o pH calculado é a variável dependente. Nas duas equações o pC é a variável independente.

A adsorção de boro pelo solo

Amostras de solos procedentes dos horizontes B2 e B3 da Série Guamium (Latosólico Vermelho Escuro-orto) e do horizonte Ap da Série Godinhos (Podzólico Vermelho-Amarelo, var. Piracicaba) do Município de Piracicaba, foram tratadas com carbonato de cálcio a fim de se obter uma variação relativamente ampla do pH. Avaliou-se a capacidade de retenção ou adsorção de boro das amostras de solos, mediante a agitação de dois gramas de material com 5 ml de soluções padrão contendo quantidades crescentes de boro. Após um repouso durante 16 horas, procedeu-se à determinação do teor de boro da solução de equilíbrio. Calculou-se a quantidade de boro adsorvida por diferença entre a originalmente existente e a determinada na solução de equilíbrio após a agitação e repouso. Os dados obtidos evidenciaram que a quantidade de boro adsorvido pelas amostras de solos estudadas aumenta com a concentração de boro da solução de equilíbrio e cresce à medida que se eleva o pH. A equação de Freundich, na sua forma linear, traduziu de um modo adequado a dependência da quantidade de boro adsorvida (log x/m ) da concentração de boro da solução de equilíbrio (log c ) e do pH do solo.

Adsorção de sulfato pelo solo

Avaliou-se a capacidade de retenção ou adsorção do ânsion sulfato por várias amostras de solos, mediante a agitação de dois gramas de material com 5 ml de soluções padrões contendo quantidades crescentes de sulfato. Após um repouso durante 16 horas, procedeu-se à determinação do teor de sulfato da solução de equilíbrio. Calculou-se a quantidade de sulfato adsorvida por diferença entre a originalmente existente e a determinada na solução de equilíbrio após a agitação da suspensão do solo e repouso. O material estudado constituiu-se de amostras de solos procedentes de vários horizontes de diversas séries do Município de Piracicaba, tratadas com carbonato de cálcio a fim de se obter uma variação relativamente ampla do pH. Os dados obtidos evidenciaram que a quantidade de sulfato adsorvido pelas amostras de solos estudadas aumenta com a concentração de sulfato da solução de equilíbrio e diminui à medida que se eleva o pH. A equação de Freundlich, na sua forma linear, traduziu de um modo adequado a dependência da quantidade de sulfato adsorvida pelo so lo (log x/m) da concentração de sulfato da solução de equilíbrio (log c) e do pH do solo.