Karyological studies on the Indian spiders IX. Chromosome constitution in two cribellate species

The haploid number of chromosomes inStegodyphus sarasinorum (Eresidae) andUloborus plumipes (Uloboridae) is thirteen (11+X₁X₂) and ten (8+X₁X₂) respectively. The sex-chromosomes are of equal size in the former and unequal in the latter. All chromosomes are acrocentric in both species.     

Cytotaxonomy of the triatominae (Reduviidae: Hemiptera)

The chromosome number and meiotic cycle of 20 species of Triatominae have been investigated. In the male, there are five types of chromosome complement: 20+XY, 20+X₁X₂Y, 20+X₁X₂X₃Y, 18+XY and 22+XY.The cytological data suggest that the type number for the subfamily is 22 (20+XY). In the hybrids: Triatoma barberi () and T. protracta (), anomalous behavior of certain chromosomes has been observed. Phylogenetic relationships based on chromosome evidence in the subfamily have been discussed. It is suggested that fragmentation is the major factor for chromosome evolution in the group.     

Optimization of polylactic-co-glycolic acid nanoparticles containing itraconazole using 2<Superscript>3</Superscript> factorial design

This study investigated the utility of a 2³ factorial design and optimization process for polylactic-co-glycolic acid (PLGA) nanoparticles containing itraconazole with 5 replicates at the center of the design. Nanoparticles were prepared by solvent displacement technique with PLGAX ₁ (10, 100 mg/mL), benzyl benzoateX ₂ (5, 20 μg/mL), and itraconazoleX ₃ (200, 1800 μg/mL). Particle size (Y ₁), the amount of itraconazole entrapped in the nanoparticles (Y ₂), and encapsulation efficiency (Y ₃) were used as responses. A validated statistical model having significant coefficient figures (P<.001) for the particle size (Y ₁), the amount of itraconazole entrapped in the nanoparticles (Y ₂), and encapsulation efficiency (Y ₃) as function of the PLGA (X ₁), benzyl benzoate (X ₂), and itraconazole (X ₃) were developed: Y₁=373.75+66.54X₁+52.09X₂+105.06X₃−4.73X₁X₂+46.30X₁X₃; Y₂=472.93+73.45X₁+ 169.06X₂+333.03X₃+62.40X₁X₃+141.49X₂X₃; Y₃= 57.36+6.53X₁+15.52X₂−12.59X₃+1.01X₁X₃+ 1.73X₂X₃.X ₁,X ₂, andX ₃ had a significant effect (P<.001) onY ₁,Y ₂, andY ₃. The particle size, the amount of itraconazole entrapped in the nanoparticles, and the encapsulation efficiency of the 4 formulas were in agreement with the predictions obtained from the models (P<.05). An overlay plot for the 3 responses shows the boundary in whichY ₁ shows the boundary in which a number of combinations of concentration of PLGA, benzyl benzoate, and itraconazole will result in a satisfactory process. Using the desirability approach with the same constraints, the solution composition having the highest overall desirability (D=0.769) was 10 mg/mL of PLGA, 16.94 μg/mL of benzyl benzoate, and 1001.01 μg/mL of itraconazole. This approach allowed the selection of the optimum formulation ingredients for PLGA nanoparticles containing itraconazole of 500 μg/mL.     

Response surface methodology for optimization and characterization of limonene-based coenzyme Q10 self-nanoemulsified capsule dosage form

The aim of this study was to systematically obtain a model of factors that would yield an optimized self-nanoemulsified capsule dosage form (SNCDF) of a highly lipophilic model compound, Coenzyme Q10 (CoQ). Independent variables such as amount of R-(+)-limonene (X ₁), surfactant (X ₂), and cosurfactant (X ₃), were optimized using a 3-factor, 3-level Box-Behnken statistical design. The dependent variables selected were cumulative percentage of drug released after 5 minutes (Y ₁) with constraints on drug release in 15 minutes (Y ₂), turbidity (Y ₃), particle size (Y ₄), and zeta potential (Y ₅). A mathematical relationship obtained,Y ₁=78.503+6.058X ₁ +13.738X ₂+5.986X ₃−25.831X ₁ ² +9.12X ₁X₂−26.03X ₁X₃−38.67X ₂ ² +11.02X ₂X₃−15.55X ₃ ³ (r ²=0.97), explained the main and quadratic effects, and the interaction of factors that affected the drug release. Response surface methodology (RSM) predicted the levels of factorsX ₁,X ₂, andX ₃ (0.0344, 0.216, and 0.240, respectively), for a maximized response ofY ₁ with constraints of >90% release onY ₂. The observed and predicted values ofY ₁ were in close agreement. In conclusion, the Box-Behnken experimental design allowed us to obtain SNCDF with rapid (>90%) drug release within 5 minutes with desirable properties of low turbidity and particle size.     

Dy(3+) and Mn(2+) emission in fluoride- and chloride-based Na(3) (SO(4) )X (X = F or Cl) phosphors

In the present study, Na₃(SO₄)X (X = F or Cl) halosulphate phosphors have been synthesized by the solid‐state diffusion method. The phase formation of the compounds Na₃(SO₄)F and Na₃(SO₄)Cl were confirmed by X‐ray powder diffraction (XRD) measurement. Photoluminescence (PL) excitation spectrum measurement of Na₃(SO₄)F:Ce³⁺ and Na₃(SO₄)Cl:Ce³⁺ shows this phosphor can be efficiently excited by near‐ultraviolet (UV) light and presents a dominant luminescence band centred at 341 nm for Ce³⁺, which is responsible for energy transfer to Dy³⁺and Mn²⁺ ions. The efficient Ce³⁺ → Dy³⁺ energy transfer in Na₃(SO₄)F and Na₃(SO₄)Cl under UV wavelength was observed due to ⁴ F_9/2 to ⁶H_15/2 and ⁶H_13/2 level, while Ce³⁺ → Mn²⁺ was observed due to ⁴ T₁ state to ⁶A₁. The purpose of the present study is to develop and understanding the photoluminescence properties of Ce³⁺‐, Dy³⁺‐ and Mn²⁺‐doped fluoride and chloride Na₃(SO₄)X (X = F or Cl) luminescent material, which can be the efficient phosphors in many applications, such as scintillation applications, TL dosimetry and the lamp industry, etc. Copyright © 2012 John Wiley & Sons, Ltd.     

Characterization of the Mixtures of Gompertz Distributions by Conditional Expectation of Order Statistics

The mixtures of Gompertz random variables (Gompertz , 1825) X₁ and X₂ are identified in terms of relations between the conditional expectation of [exp (αX_2:2) — exp (αX_1:2)]^k given X_1:2 and the hazard rate function of the distribution, k is a positive integer and α < 0. Here X_1:2 and X_2:2 denote the corresponding order statistics. In addition, we also mention some related theorems to characterize the mixtures of Gompertz distributions. Finally, when the sample size is n, the above results are also valid and we also give an application to Multi-Hit models of carcinogenesis (Parallel Systems).     

Cytotaxonomic study of Cephalota hispanica (Gory, 1833) and Spiralia maura (Linnaeus, 1758), two cicindelids from Portugal (Coleoptera)

Cephalota hispanica and Spiralia maura have similar numbers of autosomes but distinct chromosome morphology and sex chromosome systems, (9II+X₁X₂Y/9II+X₁X₂ and 9II+X₁X₂X₃Y/9II+X₁X₂X₃, respectively). The former sex chromosome system follows the pattern of Nearctic and Indian groups and the latter the Palearctic type. The chromosomal polymorphism found suggests the occurrence of other structural rearrangements in the process of differentiation of cicindelids than those usually referred to robertsonian translocations. Moreover, the polyploidy observed in males of both species suggests pre-meiotic endoreduplication phenomena.     

Characterization of the WEIBULL Distribution by Properties of Order Statistics

Let X_1:n, X_2:n, X_3:n…, X_n:n be the order statistics of n independent random variables with the common (absolutely continuous strictly increasing) distribution function F. The main results given in this article are:

• 1 For any fixed r and two distinct numbers s₁ and s₂ (1<r<s₁<s₂≦n) the distributions of V_i and W_i (defined in (1.11) and (1.12) are identical for i = 1,2 iff F(x) is WEIBULL (1.2).
• 2 The statistics D₁ and D₂ (as in (1.8) and (1.9)) are independent iff F(x) is WEIBULL (1.2).
• 3 The statistics U_i (1≦j≦n?1) and X_i:n (i ≦ j) are independent iff F(x) is WEIBULL (1.2).
• 4 Let X, X₁, X₂, …, X_k be random variables such that

These conditions are necessary and sufficient for F(x) to be WEIBULL .     

A New Approach to Equivalence Assessment in Standard Comparative Bioavailability Trials by Means of the Mann-Whitney Statistic

By a suitable transformation of the pairs of observations obtained in the successive periods of the trial, bioequivalence assessment in a standard comparative bioavailability study reduces to testing for equivalence of two continuous distributions from which unrelated samples are available. Let the two distribution functions be given by F(x) = P[X ≤ x], G(y) = P[Y ≤ y] with (X, Y) denoting an independent pair of real-valued random variables. An intuitively appealing way of putting the notion of equivalence of F and G into nonparametric terms can be based on the distance of the functional P[X > Y] from the value it takes if F and G coincide. This leads to the problem of testing the null hypothesis H_o P[X > Y] ≤ 1/2 - ε₁ or P[X > Y] ≥ 1/2 + ε₂ versus H₁ : 1/2 ? ε₁ < P[X > Y] < 1/2 + ∈₂, with sufficiently small ε₁, ε₂ ∈ (0, 1/2). The testing procedure we derive for (₀, H₁) and propose to term Mann-Whitney test for equivalence, consists of carrying out in terms of the U-statistics estimator of P[X > Y] the uniformly most powerful level a test for an interval hypothesis about the mean of a Gaussian distribution with fixed variance. The test is shown to be asymptotically distribution-free with respect to the significance level. In addition, results of an extensive simulation study are presented which suggest that the new test controls the level even with sample sizes as small as 10. For normally distributed data, the loss in power as against the optimal parametric procedure is found to be almost as small as in comparisons between the Mann-Whitney and the t-statistic in the conventional one or two-sided setting, provided the power of the parametric test does not fall short of 80%.     

The chromosomes of Schoutedenia lutea (homoptera,aphidoidea, greenideinae), with an account of meiosis in the male

Somatic chromosomes of both sexes and chromosome behaviour during spermatogenesis were studied in the aphid Schoutedenia lutea (van der Goot). Four long but unequal chromosomes in females were interpreted as X chromosomes (X₁X₁X₂X₂) with one member of an autosome pair attached to one X₁, and the other member to one X₂, so that the four long chromosomes were actually X₁+A, X₁, X₂+A, X₂. Males (normally XO in aphids) received X chromosomes corresponding in relative length to the two longest (X₁+A, X₂+A) in females. During spermatogenesis parallel pairing occurred in prophase 1 and the X₁ and X₂ chromosomes became associated via their autosomal segments. In anaphase I, the autosomal segment became detached from one of the X chromosomes and entered the non-viable (non-X-bearing) spermatocyte, while the viable spermatocyte received both X₁ and X₂ (either one of which still carried an autosome) and the haploid set of free autosomes. The consequences for sex determination and zygote formation of this unusual system are discussed; a stable chromosomal constitution for the zygote can be achieved only at the expense of considerable gamete wastage.     

Vegetation gradient on the shores of Lake Nasser in Egypt

The paper, a synthesis based on data generated by our own investigation on Stipa baicalensis steppe for the period 1986–1988, deals with the relationships among biotic and abiotic factors at community ecology level. Analysis is placed on aboveground net primary production (ANPP), the energy source for livestock production process, and on accumulated temperature (5°C) (X₁), rainfall during the growing season of the steppe plants (X₂), and content of organic matter of surface soil (X₃), the abiotic variables most often used to explain variation in ANPP.The models predicting ANPP in Stipa baicalensis steppe were structured in terms of X₁, X₂, and X₃. The predictive power of the models was found to be very high, and the models were successfully validated in three cases with an independent data set.The prediction model that gave the best fitting in Stipa baicalensis steppe was% MathType!MTEF!2!1!+-% feaafiart1ev1aaatCvAUfeBSjuyZL2yd9gzLbvyNv2CaerbqfgBHr% xAU9gimLMBVrxEWvgarmWu51MyVXgaruWqVvNCPvMCG4uz3bqefqvA% Tv2CG4uz3bIuV1wyUbqee0evGueE0jxyaibaieYlf9irVeeu0dXdh9% vqqj-hEeeu0xXdbba9frFf0-OqFfea0dXdd9vqaq-JfrVkFHe9pgea% 0dXdar-Jb9hs0dXdbPYxe9vr0-vr0-vqpWqaaeaabiGaciaacaqabe% aadaabauaaaOabaeqabaGaaeywaiaabIcacaWG4bGaaiykaiabg2da% 9iaaiwdacaaIYaGaaGioaiaac6cacaaIXaGaaG4maiaaikdacaaI4a% Gaey4kaSIaaGymaiaaikdacaGGUaGaaGymaiaaiMdacaaI0aGaaGio% aiaadIhadaWgaaWcbaGaaGymaaqabaGccqGHRaWkcaaI4aGaaGOmai% aac6cacaaI1aGaaG4naiaaicdacaaIXaGaaGimaiaaicdacaaIXaGa% amiEamaaBaaaleaacaaIYaaabeaakiabgUcaRiaaiwdacaaI3aGaai% OlaiaaigdacaaI5aGaaGioaiaaiEdacaWG4bWaaSbaaSqaaiaaioda% aeqaaOGaey4kaSIaaGymaiaaikdacaGGUaGaaGOnaiaaiodacaaI3a% GaaGynaiaadIhadaWgaaWcbaGaaGymaaqabaGccaWG4bWaaSbaaSqa% aiaaikdaaeqaaOGaeyOeI0IaaGOnaiaac6cacaaIXaGaaGOmaiaaiA% dacaaI1aGaamiEamaaBaaaleaacaaIXaaabeaakiaadIhadaWgaaWc% baGaaG4maaqabaaakeaacaqGGaGaaeiiaiaabccacaqGGaGaaeiiai% aabccacaqGGaGaaeiiaiaabccacaqGGaGaaeiiaiaabccacaqGRaGa% aeOmaiaabIdacaqGUaGaaeimaiaabIdacaqG3aGaaeynaiaadIhada% WgaaWcbaGaaGOmaaqabaGccaWG4bWaaSbaaSqaaiaaiodaaeqaaOGa% aeylaiaabodacaqG2aGaaeOlaiaabgdacaqG3aGaae4naiaabsdaca% WG4bWaa0baaSqaaiaaigdaaeaacaaIYaaaaOGaaeylaiaabccacaqG% ZaGaaeymaiaab6cacaqG0aGaaeinaiaabkdacaqG5aGaamiEamaaDa% aaleaacaaIYaaabaGaaGOmaaaakiaab2cacaqGYaGaaeOnaiaab6ca% caqGYaGaaeOnaiaabodacaqGZaGaamiEamaaDaaaleaacaaIZaaaba% GaaGOmaaaaaaaa!9ED0!\[\begin{gathered} {\text{Y(}}x) = 528.1328 + 12.1948x_1 + 82.5701001x_2 + 57.1987x_3 + 12.6375x_1 x_2 - 6.1265x_1 x_3 \hfill \\ {\text{ + 28}}{\text{.0875}}x_2 x_3 {\text{ - 36}}{\text{.1774}}x_1^2 {\text{ - 31}}{\text{.4429}}x_2^2 {\text{ - 26}}{\text{.2633}}x_3^2 \hfill \\ \end{gathered} \]We have also made, in detail, the analysis of the relationships among ANPP and 3 ecological factors above variables. ANPP was responsive to all of 3 ecological factors discussed in the paper. Action intensity, which has an effect upon ANPP, can be indicated by a contribution rate. The contribution rates of X₁, X₂, and X₃ were 1.069, 2.0513 and 1.8889, respectively.This paper not only discussed profoundly the relationships among ANPP and X₁, X₂, and X₃, but also studied exhaustively effects of the interactions X₁, X₂, and X₃, on ANPP.     

A complex sex-chromosome system in the hare-wallaby Lagorchestes conspicillatus Gould

Among specimens of the spectacled hare-wallaby Lagorchestes conspicillatus Gould (Marsupialia, family Macropodidae) 4 males had 15 chromosomes and 2 females 16 chromosomes. The sex chromosomes are X₁X₁X₂X₂ in the female and X₁X₂Y in the male, the Y being metacentric and both X chromosomes are acrocentric. In about 96% of sperm mother cells at meiosis the sex chromosomes form a chain trivalent and in more than 99% of these this orients convergently so that the X₁ and X₂ move to the same pole. Evidence is presented that L. conspicillatus has evolved from a form with 22 chromosomes including a small X and a minute Y. Autoradiographic studies show that the proximal fifth of the X₁ chromosome replicates late. This is probably the ancestral X chromosome which has been translocated to an autosome. The fate of the original Y is obscure but an hypothesis is proposed that it forms the centromeric region of the Y. A single male had 14 chromosomes and was heterozygous for a translocation involving the centric fusion of two acrocentric autosomes. In about 30% of sperm mother cells the autosomal trivalent did not disjoin regularly but, despite this, all secondary spermatocytes observed at metaphase 2 had balanced complements of chromosomes. It is assumed that unbalanced secondary spermatocytes died before reaching metaphase.     

On Asymptotically Distribution-Free Confidence Bounds for P (X1≥X2) Based on Samples not Necessarily Independent

If X₁, X₂, denote the random variables of measurement under two treatments then the probability P (X₁ ≥ X₂) is a quantity of great practical interest, especially if we consider both to be measured for the same unity. In this case the random variables cannot be assumed to be independent any longer. The following paper describes a procedure to compute approximate confidence bounds for P (X₁ ≥ X₂) where correlations between X₁, X₂ are admitted as well as between replications of the X_j. There is some relation to the FRIEDMAN-statistic with or without repeated measurements and as a special case to the sign-test. Application may be extended to ordinal data.     

Complex sex-linked fusion heterozygosity in the Australian huntsman spider Delena cancerides (Araneae: Sparassidae)

In the vast majority of spider species studied to date, the karyotype is homogeneous in morphology and exclusively telocentric. The sex-determining system consists of one to three X chromosomes in the male and, correspondingly, two to six in the female. This is the case in species of huntsman spiders belonging to the genera Heteropoda (2n=40+3X), Isopoda, Olios, and Pediana (2n=40+3X) and some populations of the colonial species Delena cancerides (2n=40+3X). In other populations of D. cancerides, wholesale fusion of the karyotype has occurred, reducing the standard huntsman karyotype of 43 telocentric chromosomes to 21 metacentrics and 1 telocentric. Eight of the centric fusion products, including an X-autosome fusion, are maintained in the heterozygous condition in males and, with the single telocentric, form a chain of nine chromosomes at meiosis. The two complexes comprising the chain behave as neo-X and neo-Y chromosomes, and thus the ancestral X₁X₂X₃X₁X₁X₂X₂X₃X₃ sex-determining system has been converted to a system of six X and four Y chromosomes in the male and twelve X chromosomes in the female. Since sex-linked complex heterozygosity is also found in a number of species of social termites, it is suggested that such heterozygosity may have adaptive significance for a colonial lifestyle. Breakdown products of the chain of nine are present in specimens of D. cancerides from Canberra and these appear to represent hybrid products between the 2n=22 and 2n=43 forms. Hybridisation may also have been involved in the origin of the chain-forming races.     

A Novel Approach to Optimize and Formulate Fast Disintegrating Tablets for Nausea and Vomiting

The aim of this study was to optimize and formulate fast disintegrating tablets (FDTs) for nausea and vomiting using aminoacetic acid, carmellose and sodium alginate with enough mechanical strength. Ondansetron HCl (water soluble) or domperidone (water insoluble) drug were added to FDTs and their disintegration behaviour was evaluated. Plackett Burman Screening Design was used to screen the independent active process variables [concentration of aminoacetic acid (X ₁), concentration of carmellose (X ₂) and tablet crushing strength (X ₃)] which were found to actively influence the dependent variables [disintegration time in the mouth (DT), wetting time (WT), and water absorption ratio (WAR)] for both the drugs. Also, the coefficients of active variables (DT, WT and WAR) of FDTs containing domperidone was found to be significantly different (P < 0.05) from the coefficients of active factors (X ₁, X ₂ and X ₃) containing ondansetron HCl FDTs. Further, FDTs containing domperidone was prepared according to central composite design for estimating the effect of active factors (X ₁, X ₂, X ₃) in extended spherical domain. The regression analysis of quadratic fit revealed that DT, WT and WAR were 98% correlated with active factors (X ₁, X ₂ or X ₃). The optimized domperidone FDTs were further compared with superdisintegrants (croscarmellose sodium or crospovidone). The data revealed that optimized domperidone FDTs were better than domperidone FDTs containing croscarmellose or crospovidone. Hence, this novel excipients combination can be used for delivery of water insoluble drugs in place of superdisintegrants.     

F-tests for Hypotheses with Block Matrices and Under Conditions of Orthogonality in the General Multivariate Gauss-Markoff Model

The multivariate general Gauss-Markoff (MGM) model (U, XB, ∑?σ²V) when the matrices V ≥ 0 and ∑ > 0 are known and the scalar σ² > 0 is unknown, is considered. The present paper is a continuation of two earlier works (Oktaba, 1988a, b). If XB = X₁Σ + X₂Δ, then the F-test for verification the hypothesis WΣA = 0 is presented. Moreover, under conditions of orthogonality the decomposition of the matrix S_A (?BCA)′L^?(?BCA) into the sum of s = r(L) matrices is given, where ?BCA is the estimator of the parametric estimable functions ?BCA, Cov (?BCA) = A′ ∑?σ²L = ?C₄?′, B? = (X′T^?X)^?X′T^?U, C₄ = (X′T^?X)^?M, where M = M′ is any arbitrary matrix such that R(X) ? R(T), T=V+XMX′; T^? is any c-inverse. R(A) is the linear space generated by the colums of A. Then under additional assumption on normality of U the statistics F for testing ?BA = 0 is deduced. Under conditions of normality of U and decomposition of S_A, the statistics F₁, …, F_s for the hypotheses jⁱ BA = 0 (i = 1,…, s) are established.     

Estimation and Verification of Hypotheses in Some Zyskind-Martin Models with Missing Values

Several theorems on estimation and verification of linear hypotheses in some Zyskind-Martin (ZM) models are given. The assumptions are as follows. Let y = Xβ + e or (y, Xβ, σ²V) be a fixed model where y is a vector of n observations, X is a known matrix nXp with rank r(X) = r ≦ p < n, where p is a number of coordinates of the unknown parameter vector β, e is a random vector of errors with covariance matrix σ²V, where σ² is unknown scalar parameter, V is a known non-negative definite matrix such that R(X) ? R(V). Symbol R(A) denotes a vector space generated by columns of matrix A. The expected value of y is Xβ. In this paper four following Zyskind-Martin (ZM) models are considered: ZMd, ZMa, ZMc and ZMqd (definitions in sec. 1) when vector y y₁ y₂ involves a vector y₁ of m missing values and a vector y₂ with (n — m) observed values. A special transformation of ZM model gives again ZM model (cf. theorem 2.1). Ten properties of actual (ZMa) and complete (ZMc) Zyskind-Martin models with missing values (cf. theorem 2.2) test functions F are given in (2.11)) are presented. The third propriety constitutes a generalization of R. A. Fisher's rule from standard model (y, Xβ, σ²I) to ZM model. Estimation of vector y₁ (cf. 3.3) of vector β (cf. th. 3.2) and of scalar σ² (cf. th. 3.4) in actual ZMa model and in diagonal quasi-ZM model (ZMqd) are presented. Relation between y? ₁ and β is given in theorem 3.1. The results of section 2 are illustrated by numerical example in section 4.     

Die Cytogenetik der Flöhe (Aphaniptera)

The phylogenetical relationship of the fleas (Aphaniptera=Siphonaptera) to the other orders of the Insecta remains unsolved. Comparative studies of the cytology of the fleas are undertaken in an attempt to elucidate this problem. Two populations of Xenopsylla cheopis Rothschild, 1903, exhibit a chromosome complement of 2n = 14 A + X₁X₂Y (male): 14 A+X₁X₁X₂X₂ (female). The X₁X₂Y-sex-trivalent is restricted to the male meiosis, in oogenesis two sex-bivalents (X₁X₁ and X₂X₂) are formed. One population of Leptopsylla segnis Schönherr, 1811 shows 2n =18 A + XY (male): 18 A+XX (female). The high chromosome number of X. cheopis, L. segnis, and N. fasciatus (Bayreuther, 1969), the diffuse premeiotic stage in the spermatogenesis of the threespecies investigated and the multiple sex-chromosome-mechanisms of X. cheopis and N. fasciatus do not support the concept of a closer phylogenetic relationship between the Aphaniptera and Nematocera, but do not preclude the possibility of a kinship of Aphaniptera and Neomecoptera. Additional studies of the cytogenetics of these two orders are required before lasting conclusions can be drawn. The analysis of the chromosome cytology of the fleas of the Marsupialia, which are considered to be the most primitive of all living forms, could prove particularly instructive.